Educational policy analysis archives

Educational policy analysis archives

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Educational policy analysis archives
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University of South Florida
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Educational policy analysis archives.
n Vol. 13, no. 42 (October 12, 2005).
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Does teacher preparation matter? Evidence about teacher certification, teach for America, and teacher effectiveness / Linda Darling-Hammond, Deborah J. Holtzman, Su Jin Gatlin [and] Julian Vasquez Heilig.
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Readers are free to copy display, and distribute this article, as long as the work is attributed to the author(s) and Education Policy Analysis Archives, it is distributed for noncommercial purposes only, and no alte ration or transformation is made in the work. More details of this Creative Commons license are available at http:/ / ses/by-nc-nd/2.5/. All other uses must be approved by the author(s) or EPAA EPAA is published jointly by the Colleges of Education at Arizona State University and the Universi ty of South Florida. Articles are indexed by H.W. Wilson & Co. Accepted under the editorship of Sherman Dorn. Send commentary to Casey Cobb ( and errata notes to Sh erman Dorn ( EDUCATION POLICY ANALYSIS ARCHIVES A peer-reviewed scholarly journal Editor: Sherman Dorn College of Education University of South Florida Volume 13 Number 42 October 12, 2005 ISSN 1068–2341 Does Teacher Preparation Matter? Evidence about Teacher Certific ation, Teach for America, and Teacher Effectiveness 1 Linda Darling-Hammond, De borah J. Holtzman, Su Jin Gatlin, and Ju lian Vasquez Heilig Stanford University Citation: Darling-Hammond, L., Holtzman, D. J., Gatlin, S. J., & Heilig, J. V. (2005). Does teacher preparation matter? Evidence about te acher certification, Teach for America, and teacher effectiveness. Education Policy Analysis Archives, 13 (42). Retrieved [date] from http://epaa.asu.ed u/epaa/v13n42/. Abstract Recent debates about the utili ty of teacher education have raised questions about whether certified teachers are, in general, more effective than those who have not met the testing and training requirement s for certification, and whether some candidates with strong liberal arts backgr ounds might be at least as effective as teacher education graduates. This study examines these questions with a large student-level data set from Houston, Texas that links student characteristics and achievement with data about their teache rs’ certification status, experience, and degree levels from 1995–2002. The data set also allows an examinatio n of whether 1 The authors would like to thank members of the Research and Accountability division of Houston Independent School District for their assistance in a ssembling the data set. We also thank researchers who provided methodological advice during the study, including Ed Haertel and Tony Bryk of Stanford University; those who read and gave comments on drafts of the report, including David Berliner and Gene Glass of Arizona State University an d Peter Youngs of Michigan State Un iversity; four anonymous reviewers and EPAA editor, Sherman Dorn, who gave the article carefu l scrutiny and provided useful feedback prior to publication. We benefited from their comments an d take responsibility for any shortcomings that remain.


Education Policy Analysis Archives Vol. 13 No. 42 2 Teach for America (TFA) ca ndidates—recruits from selective universities who receive a few weeks of training before they begin teaching—are as effective as similarly experienced certified teachers. In a series of re gression analyses looking at 4th and 5th grade student achievement gains on six diffe rent reading and mathematics tests over a six-ye ar period, we find that cert ified teachers consistently produce stronger student achievement gains than do uncertified teachers. These findings hold for TFA recruits as well as others. Contr olling for teacher experience, degrees, and student characteri stics, uncertified TFA recrui ts are less effective than certified teachers, and perform about as well as other uncertified teachers. TFA recruits who become certified after 2 or 3 years do about as well as other certified teachers in supporting student achievement gains; however, nearly all of them leave within three years. Teache rs’ effectiveness appears strongly related to the preparation they have received for teaching. Keywords: teacher educati on; teacher certification; teacher effectiveness. Introduction The relationship between teacher education and teacher effectiveness has been hotly debated in recent years in both research and policy circ les (see, for example, Ballou & Podgursky, 2000; Darling-Hammond, 2000a; Darling-Hammond & Youn gs, 2002; U.S. Department of Education, 2002). On the one hand, advocates of stronger preparation—especially for teachers in schools serving low-income students and students of color—have argued that teachers need to understand how children learn and how to make material accessibl e to a wide range of students to be successful (National Commission on Teaching an d America’s Future, 1996; Shulman, 1987). Studies finding positive effects of teacher education and certifica tion on student achievement seem to support this perspective (Betts, Rueben, & Dannenberg, 2000 ; Darling-Hammond, 2000b; Ferguson, 1991; Fetler, 1999; Goe, 2002; Goldhaber & Brewer, 20 00; Hawk, Coble, & Swanson, 1985; Monk, 1994; Strauss & Sawyer, 1986; Wenglinsky, 2000; Wi lson, Floden, & Ferrini-Mundy, 2001). On the other hand, opponents of teacher education and certification have argued that teacher effectiveness may be as much a function of general academic ability or strong subject matter knowledge as it is related to any specialized trai ning in how to teach (Ballou & Podgursky, 2000; Finn, 1999; US Department of Educ ation, 2002). Representing this view, the Secretary of Education argued in his 2002 report on teacher quality for the dismantling of teacher certification systems and the redefinition of teacher qualifications to emphasi ze higher standards for verbal ability and content knowledge and to de-emphasize education trai ning, making student teaching and education coursework optional (U.S. Department of Education, 2002, p.19). From this perspective, the courses and other expectations that make up “the bulk of current teacher certification regimes” impose “burdensome requirements” (p. 8) that keep talented individuals out of teaching. The policy implications of these debates are far-reaching, affecting teacher education and certification policies as well as policies regarding school funding and educational rights. As teacher demand has increased and funding inequities have grown over the past 15 years, many urban and poor rural districts have hired a growing number of individuals on emergency permits or waivers who lack formal preparation for teaching. These individuals typically teach low-income and minority students in the most disadvantaged schools (National Commission on Teaching and America’s Future, 1996; Shields et al., 2003). Such inequalities—and related disparities in funding and basic education materials—have spawned lawsuits in more than a dozen states arguing that all students have the right to the resources needed to learn to state standards, including fully qualified teachers.


Does Teacher Preparation Matter? 3 They also sparked the “highly qualified teacher” requi rements of the federal No Child Left Behind Act. However, if courts agree that no special training is needed for teaching, as defendants in many of these lawsuits claim, the legal levers for redre ssing these inequalities would vanish as certification standards are diluted or ignored and students’ recourse is removed. Cited in the Secretary’s report and at the center of many of these debates has been the Teach for America (TFA) program, which seeks to recrui t academically able new college graduates, many of them from selective universities, into two-yea r teaching commitments in hard-to-staff districts. Following a summer program that provides several weeks of student teaching and basic coursework, recruits are placed in urban and poor rural school s on emergency teaching permits. Although in the early years of the program recruits often taught wit hout any further training, states have increasingly required that they enter a teacher education program upon hiring and pursue coursework with supervision while they teach. Despite the increasing preparation the recruits receive both from TFA and from the formal teacher education programs mo st enter upon hiring, the program is often seen as an existence proof for the argument that br ight, committed individuals can teach successfully without formal teacher education training. Fo r example, Raymond, Luque, and Fletcher (2002) suggest: TFA corps members are an admittedly select group of college graduates, culled from the finest universities and often pe rforming near the top of their class…. It’s possible that traditiona l certification programs an d pedagogical training are less necessary for them than they are for the typical teacher. (p. 68) Several studies have sought to examine the effecti veness of TFA recruits, but none has explicitly compared the effectiveness of differently prepar ed or certified recrui ts using appropriate controls for students’ prior learning. Two stud ies have found evidence that TFA recruits’ students achieve comparable or better gains in student learni ng when compared to other similarly experienced teachers in similar sch ools (Raymond, Fletcher & Luque, 2001; Decker, Mayer, & Glazerman, 20 04), but in both of these studies the comparison group teachers were also disproportionately untrained and uncertified teachers. Neither of th ese studies explicitly compared TFA teachers to teachers with standa rd training and certific ation, controlling for other student, teacher, and school variables. A study that examined the relative effectiveness of Teach for America teachers as compared to ot her new teachers with different levels of qualifications in Arizona found that the stud ents of uncertified te achers, including TFA teachers, did less well on academic tests than those of comparably experienced certified teachers on mathematics, reading, and language arts tests (LaczkoKerr & Berliner, 2002). However, the study did not use controls for pr ior achievement of students. This study examines the question of how tea cher preparation and certification influence teacher effectiveness for both TFA and other teachers. We use a newly constructed data set from Houston, Texas that allows us to link detailed certification data on teachers to background and achievement data on students, classrooms, and sc hools for 132,071 students who were in fourth and/or fifth grade from the 1996–1997 school year through the 2001–2002 school, and their 4,408 teachers. In this article, we report on the results for these students and teachers on several different achievement tests: the TAAS, the SAT-9, and the Aprenda. Methods This study substantially replicates the results of an earlier study of TFA recruits in Houston conducted for the Hoover Institution’s CREDO center by Raymond, Fletcher, and Luque (2001). We reconstruct and then go beyond their anal yses to examine a wider range of achievement


Education Policy Analysis Archives Vol. 13 No. 42 4 measures over a greater number of years with additional controls, and we include examination of teacher certification pathways more generally. The CREDO study examined the effect of TFA teachers on student achievement gains on the TAAS reading and mathematics tests from grades 3 through 8 between 1996 and 2000. The CREDO analyses pooled the data across these years and found that, in most estimates, after controlling for teacher experience (a consisten tly strong predictor of student achievement), along with individual student, classroom, and scho ol demographics and students’ prior achievement scores, TFA recruits were about as effective as ot her teachers of comparable experience working in similar teaching settings. The study found statisti cally significant positive coefficients for TFA recruits in 2 of 10 estimates: when the studen ts of TFA recruits were compared to those of beginning teachers with 0–1 years of expe rience on the TAAS mathematics test in 4th and 5th grades and when the students of TFA teachers were compared to those of other teachers on the TAAS mathematics test in 6th through 8th grades. (Two other estimates, both in reading, were significant at the .10 level.) The effect sizes were relatively sm all: In most cases the differences represented between 1 and 5% of a standard deviation in the av erage TAAS test score. In the most positive case, TFA teachers accounted for 14% of a standard deviat ion difference in the aver age TAAS test score. The CREDO study did not examine whether TF A teachers were differentially effective when compared to traditionally prepared and certi fied teachers in Houston, although the researchers noted that certification status was one of the variable s in their data set. This question is an important one for interpreting whether and how the findings of the study may generalize to other settings with different teaching pools, because TFA teachers in Houston were compared to an extraordinarily under-qualified pool of teachers. In 1999–2000, th e last year of the CREDO study, about 50% of Houston’s new teachers (and one-third of all teacher s) were uncertified, and the researchers reported that 35% of new hires lacked even a bachelor’s degree.2 Furthermore, TFA teachers were placed in schools serving high percentages of low-income and minority students, where most under-qualified teachers in the district are placed, and where, the st udy found, students lose ground in achievement from year to year. The study’s controls for teacher experience and student characteristics at the individual, classroom, and school levels thus had the effect of drawing the comparisons largely among inexperienced and uncertified teachers. The Data Set With the assistance of the Houston Independent School District (HISD), we assembled a similar data set.3 The data set consists of information on a ll HISD teachers and students in grades 3 and higher from the 1995–1996 school year throug h the 2001–2002 school year (a total of 271,015 students and 15,344 teachers). We created a merged longitudinal data file from several files containing student-level data (demographic characteris tics and test scores on three sets of tests in reading and mathematics), teacher data (years of teaching experience, highest degree completed, certification information, and Teach for America pa rticipation), school data (student demographic information by school), and identifier data lin king students with teachers by school year. Students in the elementary grades were typica lly linked with a single teacher, presumably a teacher of a self-contained classroom teaching mathem atics, reading, and other subjects. Students in secondary grades were linked with several different teachers both within and across subject areas; 2 In a later paper, the lead author indicated that this statistic on degree status was incorrect and that the actual proportion of non-degreed teachers in Houston was likely lower. 3 We could not access the CREDO data set for re-ana lysis as, we were told, it was a “proprietary” data set.


Does Teacher Preparation Matter? 5 some had as many as 24 different teachers within a given year. Unfortunately, our data set did not allow us to match all teachers with the subjects th ey taught or to evaluate why there might be so many links for some students. The CREDO analysis eliminated many middle school students from their analysis because of these difficulties and created a “TFA intensity” ratio for the remaining students who had a TFA teacher as one of several teachers. We had a number of concerns about this methodology; consequently, we decided not to pursue an analysis of teacher effectiveness for grades 6 and above, and we limited our analysis to evaluating individual student gain scores linked to teacher characteristics in grades 3–5.Our analyses measured gains from spring of 3rd to spring of 4th grade and from 4th to 5th grade, looking at effects associated with students’ 4th and 5th grade teachers. We had a total of 223,086 records on studen ts who were in grades 4 or 5 from 1996–97 though 2001–2002.4 (A student is represented by a distinct r ecord for each year he or she is in the data base.) Links to teachers were av ailable for 212,724 of the records.5 Most of the students without teacher links were coded as "no show" or "withdrawn in the district records. In each year from 1996–97 to 2001–02, about 35,000 students were linked with teacher records.6 Variables Outcome Variables As measures of student achiev ement, we used student test scores in mathematics and reading on three separate standardized tests administered by Houston during the period studied: the Texas Assessment of Academic Skills (TAAS), the Stanford Achievement Test, 9th Edition (SAT-9), and the Aprenda. The TAAS is a state-mandated, criterion-referenced test that was administered statewide each spring from 1994 through 2002. The examinat ion was given in grades 3–8 and 10. A Spanish version was available for grades 3–6. For the TAAS the data provided by HISD contained only two metrics: (1) whether or not stud ents met minimum expectations, an d (2) the Texas Learning Index (TLI), a derived continuous score that allows for cross-year and cross-grade comparisons.7 Since we were interested in score gains, we used the TLI inde x. The TLI, however, was available only for the 4 This is a subset of the 406,036 records we had on students who were in grades 3 through 5 from 1995-96 through 2001-2002. Third graders we re part of the final analyses only if they continued in HISD through 4th grade, in which case their 3rd scores were used as controls in the regressions predicting 4th grade achievement. 5 Of the 10,362 records without te acher links, 8115 (78%) were coded with an enrollme nt status of "no show" or "withdraw." In contrast of the 212,724 records with teacher links, only 9.2% had a "no show" or "withdraw" enrollme nt status code. 6 The numbers of grades 4 and 5 students with lin ks to teachers were as follows: 35,667 in 1996-97; 35,566 in 1997-98; 33,914 in 1998-99; 34,498 in 1999-2000; 35,996 in 2000-01; 37,083 in 2001-02. 7 The TLI range was approx imately between 0 and 100 but differed by subject area and by grade each year. For example, for grade 5 math in spring 2000, the top score was 93, but for grade 5 reading in spring 2000, the top score was 101. More in formation on the TLI can be fo und on the Texas Education Agency website at ssessment/resources/techdig02/index.html (see Chapter 10, "Scaling") and ssessment/reporting/freq/index.html


Education Policy Analysis Archives Vol. 13 No. 42 6 English TAAS and not for the Spanish TAAS.8 Thus, our TAAS / TLI analyses apply only to students who took the English TAAS.9 Because of concerns raised by other research ers regarding potential score distortions on the high-stakes TAAS examinations (Klein, Hamilt on, McCaffrey, & Stecher, 2000), we were interested in alternative measures of student achievement as well. Houston began to administer national normreferenced tests in 1997–1998. The SAT-9 was administered to 1st through 11th graders who received reading and language arts instruction in English. A Spanish-language test, the Aprenda, was administered to 1st through 9th graders who received instruction in Spanish. The 1997–1998 administration was in the fall; administrations in subsequent years were in the spring. Because we wanted to look at growth over a single school yea r (e.g., spring to spring), we began our SAT-9 and Aprenda analyses with the first spring admi nistration, in 1998–1999. We used normal curve equivalent (NCE) scores to measure annual changes in student performance.10 Control Variables A variety of individual, classroom, and school factors can affect student achievement, and we attempted to control for as many of these factor s as possible in testing the influence of teacher certification and Teach for America status. To the control variables included in the CREDO study we added students’ English proficiency status, teacher degree levels, and a proxy for class size. The full set included the following: Student prior achievement We controlled for prior achievement by including in our regression models each student’s prior-year test scor e. Because our data set begins with third grade students, we looked at student performance for stud ents in fourth and fifth grades, controlling for each student’s achievement on the same test a yea r earlier. The inclusion of the prior year score variable also means that our analyses begin with the second year of data for each achievement measure (1996–1997 for the TLI, and 1999–2000 fo r the SAT-9 and Aprenda), as the first year of achievement data is used as a control. Student demographic characteristics : HISD provided data on the following student-level variables: race/ethnicity (American Indian, Asian/Pa cific Islander, African American, Hispanic, and white), eligibility for free/reduced price lunch,11 and limited English proficiency (LEP). For LEP status, the HISD data set contained several different codes representing different levels of eligibility. 8 In 1995-1996 and 1996-1997, large numbers of stud ents who took the Spanish TAAS were, apparently incorrectly, assigned a TLI of 0. These studen ts were not included in the analysis; we selected only students who took the English version. 9 The data also contained a “score code” to indicate such things as exemptions due to absenteeism, disability, and LEP; a code of “S” meant that the scor e was suitable for inclusion in calculations. Because many of the scores for students with non-S codes were apparently invalid (e.g., they were often coded as the minimum TLI value for a given test in a given grade in a given year), and because of concern about how scores of non-S coded records could be interpreted, we included in our analyses only the scores of students who had a score code of “S.” 10 We would have preferred to use scaled scores for the SAT-9 and Aprenda analyses, but scaled scores were not included in the data we received from HISD. 11 Students with all codes other th an “paid” were classified as being eligible for free/reduced price lunch; students with a “paid” code or with no code at al l were classified as not being eligible for free/reduced price lunch.


Does Teacher Preparation Matter? 7 After we conducted exploratory analyses with th ese finer categories and found that they behaved similarly, we collapsed LEP status into a binary yes/no variable.12 Teacher’s years of experience and highest degree completed : We used teachers’ total years of teaching experience as a continuous variable.13 We used two dummy variables to represent highest degree completed: bachelors degree or lo wer and masters degree or higher. Classroom level variables : The data obtained from HISD did not contain classroom-level information, but we were able to create classroom -level variables by aggregating up from the individual student-level data, using the teacher id entifier to group students. Among the classroomlevel variables we included in our analyses is the average prior year score (for all of the grades 3–5 students in the class with prior year scores). This provides an indication of the teaching context and accounts in part for the influence of peers in the learning environment. We also included the number of students in grades 3–5 in the class as a proxy for class size.14 We considered a variable characterizing the socioeconomic make up of th e classroom (the proportion of free/reduced price lunch students), but we found that this variable was highly collinear with both the individual free/reduced price lunch variable (r=.65) and the school free/reduced price lunch variable (r=.83), as well as being strongly related to the prior year achievement scores on each test. Thus, we kept the individual and school-level free/reduced price lunch variables (r=.54), but not the classroom level variable. School level demographics : The HISD data contained some school-level student demographic variables, including the school’s percentages of Af rican American students, Hispanic students, and those eligible for free/reduced price lunch. We used these three variables to capture features of the school that may be relevant both to teachi ng context and to community characteristics. 12 In exploratory analyses, we examined students whose LEP code indicated “former” or “tested but did not qualify” in addition to thos e coded “LEP” or “not LEP,” but in the final analyses, all of these students were classified as being LE P since the variables behaved similarly to the “LEP” code in regressions. 13 In our early analyses, we also examined a set of dummy variables for experience as well as an “experience squared” term that takes into account the possible non-linear nature of the experience effect. Neither of these approaches changed our results regarding teacher certification effects, but the “experience squared” term exhibited collinearity problems and made it more difficult to accurately estimate the effects of experience. We therefore op ted for the more straightfo rward continuous experience term (see Fox, 1997). 14 There were some “classes” of students associated with a given teacher that appeared to have extraordinarily small sizes, as few as one or two st udents. These could have been individual students placed in classrooms that la rgely served other grade levels (hence the number of 4th or 5th grade students’ records tied to a teacher’s record was very small), classes that were primarily tutorial situations for students with particular needs (e.g. one-on-one readin g tutorials), or classes that were very small special education classes. Because these would result in teache r effectiveness being evalua ted on tiny samples, we restricted the “classes” we included in the estimates to those with at least 15 3rd-5th grade students attached to a given teacher. In addition, because we included a term for the class average previous test scores, intended to account for contextual classroom influences, as well as a term for each individual student’s prior test score, we did not want to approach a situation in which an individual student’s test score would be weighted disproportionately as a pred ictor variable (as would be the case if a single student – or a very small number of students were attached to a given teacher and evaluated as his or her “class”). The number of students excluded by this rule was very small: for example, 699 student records were excluded from the TLI math analyses, accounting fo r 0.66% of the 106,210 total student records.


Education Policy Analysis Archives Vol. 13 No. 42 8 Teacher Preparation Pathway and Certification In exploring the influence of preparation and certification on teacher effectiveness, we had a complex set of variables to examine, represented by more than 100 certification and license codes in use in Houston. These represented both certification categories and subject matter and specialty areas in which teachers held a license. Although we would have liked to have had direct measures of teacher preparati on, such as coursework and program measures, we could use these codes to identify many aspects of the pathways teachers pursued into teaching— for example, whether teachers began teaching wi th a credential or entered as an emergency certified teacher before attaining a standard credential, whether they entered through an alternate certification program, whether they had certificati on in multiple areas (including specialty areas like bilingual education or reading), and whether they entered teaching through Teach for America. We also examined the interaction betwee n TFA status and certification, since all of the TFA teachers in our sample became certified during their tenure. Teach for America status is a straightforwar d yes/no variable. Certification status, on the other hand, is considerably more complex. Houston provided us with two different files containing data on teacher certification, each of which had a different certification coding scheme. One file contained eight different certification types, and th e other contained 13 distinct certification codes. (Any given teacher was in one of these files only.15) These different classifications were related to changes in the state and local certification systems over the study years. In addition to the types of certification, the files included the areas of certifi cation (e.g. elementary, bilingual, reading, music, counselor, etc.). We found that, for elementary teach ers, these areas of certification were very similar across teachers with standard certification (for example, most teachers secured a reading endorsement along with an elementary teachin g certificate), and after exploring the file, we concluded that adding these additional details woul d not contribute to our explanation of differences in teacher effectiveness. Finally, our data included a certification date at tached to the records of more than 75% of the teachers in grades 3–5. The certification date wa s frequently not the year of initial employment, since many teachers enter Houston schools without cer tification and secure some form of training that leads to a certification or permit later. Sin ce we were concerned with the amount and kind of training a teacher might have in a specific year, we created a year-by-year certification code for each teacher. After investigating the data, we learned th at most teachers’ certification dates were in the spring and summer months prior to a given school year. We coded teachers who were not certified by the start of a given school year (defined as August 30th) as being uncertified for that year; thus, a teacher’s certification code does not “kick in” until the school year following his or her certification date. If this decision were to bias the results, it wo uld be on the side of understating the differences in effectiveness between certified and uncertified (or “not yet certified”) teachers, rather than overstating them.16 15 An additional 293 teachers of grades 3-5 were not included in either file. No certification data was available for these teachers, so their certification is categorized as “unknown.” 16 We adopted a conservative rule for coding certification to be sure we did not artificially overstate the differences between certified and uncertified teachers This rule meant that teachers who were certified during the course of a school year (after August 30) were coded as uncertified for that year. If those who completed their preparation and/or passed their tests were more effective than others, that greater level of effectiveness would therefore be counted in the uncertif ied teacher category for that year, thus increasing the potential effectiveness measure for uncertified teachers and reducing the apparent differences between uncertified and certified teachers.


Does Teacher Preparation Matter? 9 We coded the 1558 teachers in grades 3–5 who had a certification code but no certification date as possessing their certification for all of the yea rs in which they are in the data set. We created a dummy variable, “certification date unknown,” to control for the fact that for this group of teachers, we do not know whether they actually possessed their certification in any given year. This variable takes a value of 1 for teachers without a certification date and 0 for teachers with a certification date. After researching Texas’ credentialing system and evaluating our data, we collapsed the certification types into the following categories Standard includes the standard, provisional, profe ssional, and out-of-state certificates, all of which require the completion of an approved ed ucator preparation prog ram and passage of the appropriate certification examinations.17 Alternative includes the Texas Alternative Certif ication Program (ACP) and probationary certificates, which are issued to individuals who have a bachelor’s degree, have passed subject matter tests, and are accepted into approved alternative certification programs in Texas.18 These alternative and probationary certificates are renewable for up to 3 years while the individual completes the requirements for a standard certificate. Emergency/temporary includes the categories of emergency permit uncertified, permit (teacher aide), temporary certi ficate, and recognition. These categories, used either by the state or the Houston district (which has some of its own categor ies of permits), are issued on a temporary basis to individuals who have not undertaken teacher education and who are supposed to receive mentoring and training while they are teaching. Certified out-of-field includes individuals who are “emergency permit certified”—that is, already certified but teaching out of their field of certification—and those who hold a temporary classroom permit to teach in a field other than their field of preparation. Certified, no-test includes individuals holding the school district permit or non-renewal permit granted to those who have completed preparation but not passed the state test. Uncertified is the designation we gave later-certified individuals during the years before they secured some kind of state or local certification or permit.19 Certification code missing includes individuals for whom our files held no certification code. In some analyses, we further coll apsed these categories into standa rd certification, alternative or other nonstandard certification, and uncertified. 17 The provisional and professional certificates were the Texas lifetime certif icates granted before 1999 to those who had graduated from an approved te acher education program an d passed the certification tests. The professional cer tificate was granted to individuals with a postbaccalaureate degree. After 1999, these were replaced by the standard certificate, granted for a 5 year renewable term. Out-of-state certificates are granted to individuals who hold the equivalent standard certificate in ot her states. The specific requirements for each credential can be found in the Te xas Administrative Code, Ti tle 19, Part 7, Chapter 230 and Chapter 232, available at http://info.sos.state.tx .us./pls/pub/readtac$ext 18 In Houston, about half of ACP holders are enrolled in the HISD intern program. The others attend programs at universities (e.g. Prairie View A&M, University of Houston), through the Regional office, or are enrolled in something called a “deficiency plan,” an individualized program to make up specific needs for the credential. 19 We actually created six separate “certified later, but not yet” categories, one for each of the certification codes, such that we could tell not only that a teacher was certified later, but specifically which category of certification they later received. In analyses using these variables, we found that the categories all behaved similarly. Thus, in the analyses published here, all of the “certified later, but not yet” teachers were grouped into a single category of “uncertified.”


Education Policy Analysis Archives Vol. 13 No. 42 10 Although the files included up to eight separate certification codes for each teacher, an analysis of the codes indicated that, for most teachers with multiple codes, all of the codes were in the same category (within the seven classifications listed above).20 Therefore, we based our certification variable on the first certifi cation code assigned to each teacher. TFA teachers fell into the categories of uncerti fied, alternatively certified, and standard certified teachers in different years of their teachin g careers. Despite the fact that virtually all TFA entrants are placed into the same alternative certification program upon entry, HISD coded only 6 of the 190 4th and 5th grade TFA teacher records as “alter natively certified.” The others were classified as uncertified until they completed their program. All TFA recruits were coded by Houston as “standard certified” when they completed their programs. We performed initial analyses with the separate “uncertified” and “alternatively certified” categories and found that the results were the same for these two groups. We therefore combined all of the TFA candidates prior to receipt of certification into a single category: “uncer tified / alternatively certified.” Because our goal was to look at the interaction between TFA status and certification, we examined TFA teachers by their certification category in comparison to non-TF A teachers in each categ ory of certification. Univariate statistics for all of the variables in the regressions (based on the student records actually included in the regressions) are included in Table A–1 in the Appendix. Analyses After merging our several data files and cleaning the resulting data set, we ran a series of descriptive analyses of the characteristics of stud ents and teachers and examined the distribution of teachers to students of different kinds. Then we developed ordinary least squares (OLS) regression estimates of the predictors of si x sets of student test scores (th ree tests with two subject areas for each), both with data pooled across all of ou r study years and for each year individually.21 In each set of estimates, conducted at the individual studen t level, we controlled for prior year test scores, student race/ethnicity, poverty, and language stat us; teacher years of experience and degree level; class size and class average previous year’s test sc ore; and school demographics (the percentages of students who were African American, Hispanic, and those eligible for free/reduced price lunch). Key independent variables were teacher certification status and TFA status. These analyses were helpful for comparing our results to those of the earlier CREDO study, which used similar methods. Because we were also c oncerned about the influences of classroom and 20 Of the 15,344 total teacher cases in our file 8756 had only a single certification code. Of the remaining 6588, 2084 had the same certification code for their second cer tification area as for their first and 4504 had codes that were different only because of the chan ge in state terminology fo r the standard certificate before and after 1999. The “standard,” “provisional,” and “professional” codes are the different terms given to certificates for fully prepared teachers before and after a major certification reform in 1999. Of the remaining 460, many had non-standard codes that were also e quivalent versions of different state and local terms used before and after 1999 (e.g. 67 teachers coded as emergency uncertified/sch ool district permit and 61 coded as ACP/probationary). Thus, we used only a single certification code for each teacher. Among 2104 teachers of grades 3-5 who had first code of “pro visional,” 1488 had a second cer tification code. For 781 of these teachers, the second co de is also “provisional”; for 694, the seco nd code is “professi onal.” In line with the state rules, we categorize all of these as “standard” certificates. 21 The numbers of records for 4th and 5th grade student taking – and teachers administering—each of these tests included more than 100, 000 student records and 4,000 teacher re cords for those pa rticipating in the TAAS tests over 6 years, more than 60,000 st udent records and 2,000 te acher records for those participating in the SAT-9 tests ov er 3 years, and more than 11,000 stud ent records and 750 teacher records for those participating in the Aprenda tests over 3 years.


Does Teacher Preparation Matter? 11 school contextual effects in a nested data set like this one, we conducted a set of preliminary analyses using hierarchical linear modeling (HLM) techniques, which are presented in Appendix C. They confirm the general findings of the OLS analyses. Results Descriptive Statistics Our data set closely reflects both published data about the Houston Independent School District and the CREDO data. We summarize here data on the 4th and 5th grade students and teachers who are the focus of our analysis. Table 1 shows 4th and 5th grade student enrollments by race/ethnicity, language background, and socioeconomic status for each of the years in our study. Hispanic students in Houston comprise a majority of the population, followed by African American students, who comprise about a third of the studen t body. About three-quarters of the students are eligible for free or reduced price lunch. Before 1998, about 12% of students were classified as limited English proficient, but the proportion ju mped to over one-third from 1998–99 on. Our conversations with Houston staff suggested that this was due to a change in classification practices between 1997–98 and 1998–99, rather than a change in student demographics. Table 1 Student Demographic Characteristics, Houston ISD, Grades 4–5 Population Group 1996–971997–981998–99 1999–002000–01 2001–02 American Indian 0.1%0.1%0.1% 0.1%0.1% 0.1% Asian/Pacific Islander 2.6%2.7%2.8% 2.9%2.9% 2.8% African American 33.8%33.7%33.8% 33.7%32.8% 32.6% Hispanic 51.1%51.9%52.4% 52.1%53.3% 54.8% White 12.4%11.7%10.9% 11.3%10.9% 9.7% Free/Reduced Lunch 74.7%72.7%76.7% 71.1%72.5% 75.0% Limited English Proficient 11.0%12.2%34.4% 37.5%40.3% 42.1% Total (N) 37,39637,53634,589 36,62238,015 38,928 Houston’s teaching force for these years was less experienced than most. (See Table 2.) Nationally, the teaching force averaged about 15 years of experience during these years, and about 5 percent of all teachers were brand new to teaching. In Houston, beginning teachers (with less than 2 years of experience) were a large and growing share of the teaching force, increasing from 14% to 23% of teachers from 1996 to 2002. Teachers with six or more years of experience decreased from 64% to 57% during that time. Most teachers he ld bachelors degrees, with the proportion of such teachers increasing from 68% to 75% from 1996 to 2002 and the share with masters degrees declining at about the same rate, from 31% in 1996 to 23% in 2002.


Education Policy Analysis Archives Vol. 13 No. 42 12 Table 2 Teacher Experience and Degr ees, Houston ISD, Grades 4–5 Trait 1996–97 1997–981998–991999–002000–012001–02 Experience 0–1 year 14.2% 15.0% 19.0% 18.4% 19.2% 22.7% 2–5 years 21.6% 19.8% 16.8% 18.8% 19.9% 20.5% 6–10 years 19.0% 18.0% 18.4% 17.7% 16.5% 15.3% 11+ years 45.2% 47.2% 45.8% 45.1% 44.4% 41.5% Highest Degree < Bachelors 0.5% 0.2% 3.5% 3.8% 5.5% 0.6% Bachelors 67.6% 69.2% 66.4% 68.7% 67.4% 75.0% Masters 30.9% 29.9% 28.9% 26.4% 25.5% 23.2% Doctoral 0.8% 0.7% 1.1% 1.1% 1.6% 1.2% Total N 1,841 1,802 1,617 1,770 1,805 1,794 Note: Includes all teachers who taught any 4th or 5th grade students. We also looked at the certification status of TFA and non-TFA teachers for each year of the study. (See Figure 1, below, an d Table A–2 in the Appendix.) 56.5% 65.2% 61.6% 68.6% 65.4% 67.8% 48.3% 68.7% 45.7% 64.8% 45.2% 73.1% 0% 10% 20% 30% 40% 50% 60% 70% 80% Non-TFATFANon-TFATFANon-TFATFANon-TFATFANon-TFATFANon-TFATFA 1996-971997-981998-991999-002000-012001-02 Percent of Teachers Holding Standard CertificationFigure 1 Certification Status of HISD Teachers 1996-2002 Strikingly, in each year of th e study, the proportion of teachers in these grade levels teaching without standard certification ranged from one-third to nearly half. In the early years of the study (1996–1998), Teach for America teachers appeared to be as likely as other teachers in these grade levels to hold standard certification.22 From 1999–2001, Teach for America teachers were noticeably 22 We note that about 16% of teacher records with certification codes lacked certification dates in the personnel file for 1996-97, and about 13% lacked certi fication dates in 1997-98, which makes us unwilling to


Does Teacher Preparation Matter? 13 less likely to hold standard certification than other teachers. As we describe later, the dramatic shift in the relative qualifications of TFA teacher s and other Houston teachers between 1998–99 and 1999–00 may be related to changes in their rela tive effectiveness as reflected in our regression estimates for different years. These certification patter ns are related in part to the experience levels of TFA recruits, who make a two-year commitment to teaching. Most TFA recruits are placed in a teacher education program upon arrival (with f ew exceptions, this is the Houston alternative certification program), and most are certified after one or two years. In our data set, TFA recruits were certified by their second or third year of teaching. The Houston program is designed to provid e beginning teachers with weekly training sessions run by the district and a mentor at their school, as well as release time to observe other teachers once a month. The recruits take teacher education courses at a local university; in recent years the University of St. Thomas has offered up to six courses in the certification program and an expanded master’s degree at a discounted rate for those who want to pursue additional study. The program is designed to be finished in a year; ho wever, many TFA recruits in our data base did not become certified until their third year of teaching. This may be a function of taking additional time to complete courses or pass the requisite certifi cation tests, or because some recruits did not complete the program. 56% 60% 66% 68% 64% 61% 53% 58% 63% 64% 64% 62% 57% 64% 73% 77% 76% 76% 0% 10% 20% 30% 40% 50% 60% 70% 80% 90% 1996-19971997-19981998-19991999-20002000-20012001-2002Percent of teachers with standard certification African American Hispanic WhiteFigure 2 Proportion of HISD Students Taught by Teachers with Standard Certification We found that teachers without standard certification, including TFA teachers, were disproportionately likely to be teaching African American and Latino students and low-income draw strong conclusions about when teachers acquired their certification in these years. In subsequent years, the numbers of files with certification codes but without certification dates dropped sharply, totaling only 6.5% in 1998-99, 4.5% in 1999-00, 2.9% in 2000-01, and 1.8% in 2001-02. We have greater confidence in the certification dates for these years.


Education Policy Analysis Archives Vol. 13 No. 42 14 students. Although the percentages of Houston studen ts being taught by standard-certified teachers rose substantially over the years covered by this study, the racial/ethnic and economic disparities associated with students’ access to certified teach ers also increased substantially. In 1996–1997, for example, 56% of black students and 57% of whi te students were taught by standard certified teachers, a difference of less than 1%. By 2001–200 2, 76% of white students had standard-certified teachers, while only 61% of black students did—a difference of 15%. (See Figure 2.) Similarly, in 1996–97, 54% of low-income students (those eligib le for free or reduced price lunch) had teachers who held standard certification, as compared to 57% of students not eligible for free or reduced price lunch, whereby 2001–02, the proportions were 61% and 72%, respectively. This suggests that as Houston hired and retained greater numbers of certified teachers, these teachers were disproportionately distributed to higher-income students and white students. Like the CREDO study, we found high rates of attrition for TFA teachers, which were higher than those for other HISD beginning teach ers. Raymond and colleagues reported that across the four years of their study, TFA teachers had left teaching in Houston by their third year at rates of between 60% and 100%. We found similar attrit ion rates: Between 57% and 90% of TFA recruits had left teaching in Houston after their second year, and between 72% and 100% of recruits had left after their third year. (See Table 3.) Table 3 Attrition Rates of Beginning Teachers, Houston ISD, 1996–9 7—1998–99 cohorts After two years After three years Grade level and cohort TFA Non-TFATFA Non-TFA Grades 4–5 1996–97 entrants 90.0% 42.6% 100.0%48.5% 1997–98 entrants 64.3% 30.9% 78.6%31.6% 1998–99 entrants 57.1% 44.8% 100.0%54.6% All Grades 1996–97 entrants 80.8% 36.4% 96.2%44.5% 1997–98 entrants 64.0% 23.2% 72.0%35.3% 1998–99 entrants 57.7% 51.2% 84.6%54.8% Thus, although a substantial proportion of TFA r ecruits became certified within two or three years, few stayed in the district after they had completed their initial preparation for teaching. Generally rates of attrition for TFA teachers wer e about twice as high as for non-TFA teachers. Attrition rates for newly hired non-TFA teachers ranged between 32% and 55% after three years. We note that all beginning teachers had a somewhat higher attrition rate in 2000–01 (the third year of teaching for 1998–99 entrants), which may have been a function of either reductions in force in Houston or particularly difficult teaching conditions that resulted in many new teachers’ leaving. Analyses of Teac her Effectiveness The General TFA Effect Although our data set differed in minor ways from that used by the CREDO research team, and we controlled for several additional variables of ten found to influence achievement (students’ English proficiency, teacher degree levels, and class size), we achieved similar results: When we


Does Teacher Preparation Matter? 15 examined the effects of TFA status on student ac hievement gains on the TAAS tests for the pooled years 1996–97 to 2001–02—controlling for prior student achievement, student demographic characteristics, and teacher characteristics—we fo und that TFA teachers exerted a positive effect on achievement on the TAAS/ TLI in math and a nonsignificant effect on the TAAS/ TLI in reading. However, when we looked at other test measures and for individual years, the results were quite different. On the SAT-9 and Aprenda, TFA teachers had a negative effect on student scores in both math and reading. (See summary in Table 4. The full model is presented in Appendix B–1.) Table 4 Teach for America effects in multip le regressions, Housting ISD, by Test (pooling across years) Statistic TLI Math TLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading TFA coefficient (Unstandardized) 0.689*** -0.039 -0.882** -0.642* -2.87** -2.58** T-value (3.98) (-0.184) (-2. 74) (-2.08) (-2.88) (-2.61) Effect Size 0.066 -0.003 -0.046 -0.03 -0.174 -0.156 R2 .43 .39 .62 .68 .42 .43 N 105,511 103,122 60,488 60,607 11,437 11,436 *p<.05; **p<.01; ***p<.001 T-values are in parentheses. Equations control fo r student’s previous year’ s test score, student race/ethnicity, free/reduced price lu nch status, and LEP status; teacher years of experience, degree level, certification date unknown; class number of students, class average previous year’s test score, school demographics (racial/ethnic composition and poverty). We found that TFA effects varied by year of the tests. (See Table 5.) Table 5 Teach for America effects in multiple regressions, Housting ISD, by Test and Year Year TLI Math TLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading 1996–97 1.48** (2.77) -0.075 (-0.118) — — — — 1997–98 1.34** (2.85) 0.300 (0.569) — — — — 1998–99 2.83*** (5.27) 2.42*** (3.76) — — — — 1999–00 -0.727~ (-1.62) -1.16* (-2.08) -0.769 (-1.17) -1.34* (-2.12) -1.04 (-0.752) 1.04 (0.739) 2000–01 0.286 (0.957) -0.690 (-1.62) 0.152 (0.270) 0.426 (0.804) -3.99* (-2.38) -2.73 (-1.64) 2001–02 -0.353 (-1.47) -0.972** (-2.70) -1.61** (-3.33) -0.904~ (-1.91) -6.21** (-3.26) -8.71*** (-4.06) ~ p <.10; *p<.05; **p<.01; ***p<.001 T-values are in parentheses. Equations control for: student’s previous year’s test score, student race/ethnicity, free/reduced price lu nch status, and LEP status; teacher years of experience, degree level, certification date unknown; class number of students, class average previous year’s test score, school demographics (racial/ethnic composition and income).


Education Policy Analysis Archives Vol. 13 No. 42 16 On the TAAS math tests, the positive effects found in the overall analysis by both CREDO and us held only for the years 1996–97 through 1998– 99. Starting in 1999–2000, the point at which TFA teachers were noticeably less likely to be certifie d than other teachers in these grade levels, the TFA coefficient in math became non-signific ant. In reading on the TAAS, where the TFA coefficient in the pooled years analysis had b een non-significant, th e TFA coefficients were significant and positive in 1998–99, the year in wh ich TFA recruits were much more likely to be certified than other Houston teachers. (See Table A–2 in the Appendix.) The coefficients in reading were significant and negative in two of the th ree years between 1999–00 and 2001–02, when TFA recruits were much less likely than other Houston teachers to be certified. On the SAT-9 and Aprenda, which were given only in the years after 1998–99, TFA coefficients were non-significant or negative. By 2001–02, the coefficients for TFA were negative across the board. Thus, examined across measures and individual years, the TFA coefficient is positive on the TAAS in mathematics only in the first three years of the six years of data we analyzed and on the TAAS in reading only in 1998–99, the year when TFA recruits were better qualified than other Houston teachers.23 In this year, 73% of TFA teachers had standard certification, as compared to only 65% of other Houston teachers. This is probably because that year’s TFA cohort included a greater share of more experienced members who ha d completed their preparation. In the following year (1999–2000), however, only 48% of TFA recruits held standard certification as compared to 68% of other Houston teachers. At this point and thereafter the observed effect of TFA recruits relative to other teachers shifted to nonsignificant or negative on each test. These year-by-year analyses point out how the TFA effect varies according to the relative qualifications of TFA candidates and others in Houston schools. We pursue this further in the analysis below that examines TF A status by certification status. The differences we observed in the influences of TFA status across tests may have been a function of differences in the tests. For example, the SAT-9 is generally considered a more rigorous test more focused on higher level thinking skills than the TAAS, and because it was not a highstakes test in Houston, it may have been less subject to distortions caused by teaching to the test. (We note also that our equations predicted much mo re of the variance in the SAT-9 tests than the TAAS, which may also be a function of the different positions of the two tests in the accountability system in Houston.) It is also possible, though, th at the differences in outcomes were a function of the years in which the tests were offered, sin ce the SAT-9 and Aprenda were administered and analyzed in the years after 1998–99, when TFA recr uits were, as a group, less well qualified, and were also found to be less effective than other teachers in producing student gains on the TAAS. The Effects of Certification Using the same basic models, we also examined the relationship between teacher certification and teacher effectiveness. First we lo oked at the effects of different certification categories on teacher effectiveness, irrespective of TFA status. Then we examined the interaction of certification and TFA status. We found that, relative to teachers with standard certification, uncertified teachers and those in most other non-standard certification categor ies generally had negative effects on student achievement, after controlling for student characteris tics and prior achievement, as well as teacher experience and degrees. Uncertified teachers showed significant negative effects across five of the 23 Because the sample sizes for TFA candidates are relatively small in any given year (about 30 recruits), we did not calculate effect sizes for these coefficients.


Does Teacher Preparation Matter? 17 six tests. Teachers with missing certification codes (who are likely to be uncertified) also showed significant negative effects on student achievemen t on four of six tests. Similarly, teachers who were certified without passing the state teacher certification tests (a speci al permit category in HISD: such teachers would classified as uncertified in other districts that do not offer such a permit) showed negative effects across four of six tests, plus one mo re at the .10 level of significance. (See Table 6 for a summary and Table B–2 in the Appendix for the full model.) Table 6 Teacher Certification Status and Student Achievem ent Gains, Houston ISD Grades 4–5, by Test (pooled across years) Certification status TLI Math TLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading Uncertified -0.525*** (-8.03) [-0.05] -0.580*** (-7.23) [-0.05] -0.414** (-3.30) [-0.02] -0.516*** (-4.31) [-0.03] -1.41*** (-4.61) [-0.09] -0.066 (-0.216) [-0.003] Alternative certification -0.897* (-2.02) [-0.09] -0.818 (-1.49) [-0.07] -2.31** (-3.29) [0.12] -1.40* (-2.09) [-0.07] -0.491 (-0.454) [-0.03] 3.13** (2.91) [0.19] Emergency/ temporary certification -0.701*** (-3.85) [-0.07] -0.690** (-3.07) [-0.06] -0.636~ (-1.68) [-0.03] 0.780* (2.16) [0.04] -1.40 (-1.15) [-0.08] -0.754 (-0.619) [-0.05] Certified, but out-of-field 0.667* (2.52) [0.06] 0.902** (2.77) [0.07] -1.80*** (-4.36) [-0.09] 0.216 (0.548) [0.01] -3.96** (-2.64) [-0.24] 3.64* (2.45) [0.22] Certified, no test -0.187 (-0.655) [-0.02] -0.655~ (-1.87) [-0.05] -4.49*** (-7.06) [-0.23] -2.34*** (-3.83) [-0.12] -3.52*** (-3.66) [-0.21] -4.76*** (-5.01) [-0.29] Certification code missing 0.113 (0.549) [0.01] -0.642* (-2.53) [-0.05] -2.26*** (-4.63) [-0.12] 0.121 (0.260) [0.01] -4.78*** (-3.84) [-0.29] -4.37*** (-3.52) [-0.26] R2 .43 .40 .62 .68 .42 .43 N 105,511 103,122 60,488 60,607 11,437 11,436 ~p<.10, p < .05, ** p < .01, ***p< .001. T-values ar e in parentheses; effect sizes are in brackets. The reference group is standard-certified teachers. Equations control for student’s previous year’s test score, student race/ethnicity, free/reduced price lunch stat us, and LEP status; teache r years of experience, degree level, certification date unknown; class number of students, class average previous year’s test score, school demographics (racial/ethnic composition and poverty). The influences were a bit more mixed in the ot her categories. Alternatively certified teachers had negative effects on achievement on three tests. On the Aprenda in reading, alternatively certified teachers had a significant positive effect. Since th e Houston alternative certification program enrolls a substantial number of Hispanic teachers, it ma y be that more of these teachers are Spanishspeaking and able to support the literacy progre ss of Spanish-speaking students who take the Aprenda. Teachers on emergency or temporary cert ificates showed negative effects on student achievement on three tests; however, they showed a positive effect on the SAT-9 in reading. Interestingly, teachers who were already certified but credentialed to teach out of field had significant positive effects on two out of three reading tests and one mathematics test (the TAAS/TLI in reading and math and the Aprenda in reading, with a positive coefficient on the SAT-


Education Policy Analysis Archives Vol. 13 No. 42 18 9 in reading as well), but significant negative effects on the other two math tests (the SAT-9 and Aprenda). Overall, teachers without certi fication or with non-standard certification were found to be less effective in raising student test scores than teachers with standard certification in 22 of 36 estimates (p<.10). In general, relative to teacher s with standard certification, teachers lacking full certification slowed student progress over the course of a year by about to 1 month in grade equivalent terms on most achievement tests. However, some categories of teachers with substandard certification (those who had not passed the certifi cation tests or who had no record of being certified) had an even larger negative effect on the Spanish-speaking students who took the Aprenda, slowing their progress by 2 to 3 months within a year in comparison to the progress they would be expected to make with a fully certified teacher. The effects of certification status were generally much stronger than the effects of tea cher experience. For example, on the SAT-9 and Aprenda tests, the positive effect of an additional ye ar of teacher experience was about one-tenth the size of the effect of having a fully certified teacher. The Combined Effects of TF A and Certification Status In Table 7 we display the results for Teach for America teachers within different certification categories considered in relation to non-TFA st andard certified teachers and other differently certified non-TFA teachers. (The full model is pres ented in Table B–3 in the Appendix.) Again we found that uncertified teachers and those with less than standard certification—whether TFA or non-TFA—exert negative effects on student achiev ement relative to teachers with standard certification.24 Uncertified TFA teachers showed significan t negative effects on student achievement in five of six estimates (and the sixth also ha s a negative coefficient.) The same was true for uncertified teachers who were not members of Teach for America. For non-TFA teachers, those with nonstandard certifications (alternative, emer gency, temporary, or certified without having passed the test) also showed negative influences on achievement that are significant at the .10 level or below in four of six estimates. On all tests but one (the TAAS math test), the negative effect of having an uncertified TFA teacher was greater than the negati ve effect of having an uncertified or nonstandard certified teacher who was not recruited through TFA, depressing st udent achievement by between one-half month to 3 months annually compared to a fully certified teacher. For other categories of less than fully certified teachers the negative effects generally ranged from about 0.2 month to 1.5 months, depending on the test. Because certification status ma y be correlated with experience, especially in the first year or two, we also conducted estimates using dummy variables for experience, including a control for teachers with 0 to 1 years of experience, and got similar results with similar effect sizes.25 24 All TFA teachers had one of three certification types: uncertified or alternatively certified before they completed their certification program and standard certified after they had completed the program. We combined the six TFA teachers who were coded by HISD as “alternatively certified” with the others who were not yet certified for the year(s) before they receive d standard certification. We grouped all other teachers into the following categories: uncertified, alternative plus all other nonstandard certification categories, and standard certified (including certified, out-of-field). 25 We used experience categories 0-1 years, 2-5 years, 6-10 years, and 11 or more years. In all cases, teachers with 0 to 1 year of experience had a strong negative effect on student achievement. After controlling for this, uncertified TFA teachers had a negative effect in 5 estimates (one of these was marginal at p<.10) and a non-significant effect in one estimate relative to non-TFA standard certified teachers. Uncertified nonTFA teachers also had a negative effect in 5 estimates and a non-significant effect in one.


Does Teacher Preparation Matter? 19 Table 7 Teacher Certification Status, TFA Status, and Student Achievement Gain s, Houston ISD Grades 4–5, by Test (pooled across years) Certification and TFA Status TLI Math TLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading TFA teacher, uncertifieda -0.288 (-1.14) [-0.028] -1.22*** (-3.93) [-0.099] -1.89*** (-4.41) [-0.099] -1.09** (-2.67) [-0.055] -4.06** (-3.01) [-0.246] -5.09*** (-3.81) [-0.301] TFA teacher, standard certified 1.18*** (4.93) [0.113] 0.437 (1.49) [0.035] -0.008 (0.017) [-0.0004] -0.458 (-0.994) [-0.023] -2.55~ (-1.73) [-0.154] 0.839 (0.572) [0.051] Non-TFA teacher, uncertified -0.488*** (-7.36) [-0.047] -0.550*** (-6.76) [-0.045] -0.341** (-2.68) [-0.018] -0.519*** (-4.25) [-0.026] -1.33*** (-4.30) [-0.080] -0.014 (-0.045) [-0.001] Non-TFA teacher, nonstandard certified -0.284 (-1.63) [-0.027] -0.605** (-2.81) [-0.049] -1.54*** (-4.60) [-0.081] -0.051 (-0.159) [-0.003] -2.45*** (-3.53) [-0.148] -1.26~ (-1.83) [-0.076] R2 .43 .40 .62 .68 .42 .43 N 105,511 103,122 60,488 60,607 11,437 11,436 ~p<.10, p < .05, ** p < .01, ***p< .001. T-values are in parentheses; effect-sizes are in brackets. aIncludes the six TFA teachers coded in the alternativ e certification category. Al l of these teachers were coded by HISD and by us as standard certified when they co mpleted their certification program. Reference group is non-TFA standard -certified teachers. Equations control for student’s previous year’s test score, student race/ethnicity, free/reduced pr ice lunch status, and LEP status; teacher years of experience, degree level, certification date unknown; class number of students, class average previous year’s test score, school demographics (racial/ethnic composition and poverty). Relative to other teachers with standard certification, TFA teachers with standard certification did about as well, with only two statisti cally significant differences. As signaled in the CREDO analyses and ours, certified TFA teachers di d better than other standard certified teachers in supporting student achievement on the TAAS test in mathematics, increasing student achievement by just over 1 month in grade equiva lent terms during the course of a year. On the other hand, TFA teachers’ students did marginally worse than students of other standard certified teachers (p<.10) on the Aprenda in mathematics, laggi ng in achievement by about 1.5 months over a year’s time. In another analysis of these data, summarized in Appendix C, hierarchical linear modeling (HLM) techniques were used to take into account the nesting of students within classrooms and of classrooms within schools. The findings of this analysis were similar to the OLS findings: 4th and 5th grade students taught by uncertified TFA teacher s performed less well on three tests (TAAS reading, SAT-9 reading, and Aprenda math) than the st udents of non-TFA standard certified teachers (controlling for student prior test scores, teacher experience and degrees and student / school characteristics); coefficients on the other three tests were also negative but not significant. Non-TFA uncertified teachers had negative effects, relative to non-TFA standard certified teachers, on four of the six tests and insignificant effects on the other two. Students of certified TFA teachers performed comparably to students of other certified teacher s on all six tests, with no statistically significant differences.


Education Policy Analysis Archives Vol. 13 No. 42 20 Overall, then, teachers’ abilities to support st udent achievement appear to depend, both for TFA teachers and others, substantially on the level of preparation these teachers have had, as reflected in their certification status. Discussion Although a number of studies have found that students taught by fully certified teachers appear to achieve at higher levels, few have been able to examine individual student-level data over multiple years on multiple measures with appr opriate controls. Previous studies of Teach for America, as a specific pathway into teaching, have either failed to control for certification status or for students’ prior achievement in examining the outcomes of this program on teachers’ effectiveness. Our ability to look at these questions using a large data set that represents these teacher variables and a range of student, classr oom, and school controls has provided a unique opportunity to evaluate how teacher education and pathways into teaching may influence teacher effectiveness. Of course, certification is only a proxy for the real variables of interest that pertain to teachers’ knowledge and skills. These include knowle dge of the subject matter content to be taught and knowledge of how to teach that content to a wide range of learners, as well as the ability to manage a classroom, design and implement instructi on, and work skillfully with students, parents, and other professionals. In Texas, teachers who have achieved standard certification are required to have passed tests of core academic skills in co mmunications and mathematics, tests of specialized subject matter knowledge, and tests of pedagogi cal knowledge. They also have completed an approved teacher education program which includes specified courses in the content area(s) to be taught as well as coursework in teaching and learning; instructional methods and strategies; classroom management; curriculum; measurement an d evaluation of student learning; human growth and development; multicultural education; the education of special needs students; legal and ethical aspects of teaching; organization of schools; technology; and the teaching of reading (Texas Administrative Code, Title 19, Pa rt 7, Rule 230.191, 2004). This array of requirements, in combination, appears to make a difference in teacher effectiveness. Like other studies cited earlier, we find that 4th and 5th grade teachers in Houston who hold full certification—the professional or standard certificate Texas awards to recruits who have graduated from an approved teacher education pr ogram—are more effective than other teachers in stimulating student achievement gains in both reading and mathematics on three different test batteries over a multi-year period. This relationship holds whether the teachers are recruited through Teach for America or through other pathways. Those who have completed the training that leads to certification are more effective than those who have not. Although some have suggested that perhaps bright college graduates like those who join TFA may not require professional preparation for teaching, we found no instance where uncertified Teach for America teachers performed as well as standard certified teachers of comparable experience levels teaching in similar settings. In the OLS estimates, on 5 of 6 tests, uncertified TFA teachers showed a significant negative effect on student achievement gains relative to standard certified teachers. (The sixth coefficient was also negative but non-significant.) The effect sizes are noticeable: Over the course of a year, students ta ught by uncertified TFA teachers could be expected to achieve at levels that are, in grade equiva lent terms, one-half month to 3 months lower than students taught by teachers with standard certi fication. Those taught by other teachers who are uncertified or who hold nonstandard certification generally achieve at levels 0.2 to 1.5 months behind their counterparts taught by standard certified teachers. Students in the most impacted


Does Teacher Preparation Matter? 21 schools, who have a steady parade of such teachers each year, would generally lose 1 to 2 years of ground in grade equivalent terms between kindergarten and 6th grade, assuming the effects we found for 4th and 5th grades generalize to other grade levels. At the same time, Teach for America teache rs who had achieved standard certification generally performed on a par with other certifi ed teachers, after controlling for degrees and experience, as well as a variety of student and school factors. They were more effective than other certified teachers on one of the six measures we examined (the TAAS mathematics test) and marginally less effective (p<.10) on anot her (the Aprenda mathematics test). We were able to confirm these general findings with an HLM analysis that essentially replicated our analyses of certification and TF A status on student achievement using data pooled across years. However, it would be useful in future work to use hierarchical linear modeling in a longitudinal framework that tracks teachers’ effecti veness across years or to explore functional data analyses that allow consideration of teachers’ deve lopmental career paths as they unfold over time. This would allow consideration of a number of other questions: Do some categories of teachers become more effective than others as they ga in education and experience? How much of the apparently stronger performance of groups of teachers as they achieve certification or gain experience is a function of enhanced effectiveness an d how much is actually a selection effect caused by weaker candidates dropping out of the data set as they leave teaching after a period of time? What are the cumulative effects for students of havi ng different kinds of teachers with different configurations of training and experience over multiple years? The Successes and Limitations of TFA and Other Pathways in the Houston Context This study, in combination with the findings of the CREDO study, suggests some successes and limitations of both the Teach for America prog ram and other alternative programs in Houston. Across the country, Teach for America operates only in districts that, for a variety of reasons, hire many uncertified teachers. During the years stud ied, Houston was such a district, although there were improvements in the recruitment of certified teachers over the years studied (from about 56% of teachers in 1996 to 67% in 2001). Our analyses suggest that in contexts wher e many teachers have little preparation for teaching and where there is high turnover, TFA may make a positive contribution. The Teach for America organization often notes that its goal is to bring stability for at least one or two years to classrooms in poor and minority schools that might ot herwise have a parade of substitute teachers, and argues that its recruits do as well as other teachers these students might have. Given the likelihood that these students would otherwise have equally inexperienced and uncertified teachers, this claim seems to be at least partially suppor ted by our data. Entering TFA teachers appear to perform about as well as other uncertified tea chers in Houston on at least some tests, after controlling for experience, degree status, and studen t characteristics. Most of them stay for two years, which may provide a modest degree of stabili ty to schools that might otherwise experience an even more quickly revolving door for teachers in and out of classrooms. It might also be argued that the reputedly st rong liberal arts background of TFA teachers may contribute to their students’ relatively better showing on the TAAS mathematics tests. On this one test—though not on the other two mathematics tests used in Houston (the SAT-9 and the Aprenda)—the students of fully certified TFA r ecruits performed significantly better than the students of other certified teachers. Given th e longstanding concerns about the mathematics background of many elementary school teachers, it would be plausible that candidates who have attended relatively selective colleges would have a stronger basic mathematics background in high school and college than the average elementary teach ing candidate. That this effect did not hold up


Education Policy Analysis Archives Vol. 13 No. 42 22 on the SAT-9 and the Aprenda may be a function of di fferences in what the tests measure or of the quality of the TFA cohorts in the later years of our study, when the SAT-9 and Aprenda were administered. The strength of TFA cohorts may differ from yea r to year, as the prog ram’s recruitment and training practices fluctuate. The strongest positive TFA effects were in 1998–99, when TFA candidates were much more likely to be certified than the average Houston teacher. The most negative year was 2001–02, when TFA recruits had negative effects on student achievement on 5 of 6 tests. In addition to the fact that TFA teachers were much less likely than other Houston teachers to be certified in this year, there may have been other selection or traini ng effects operating. The TFA program has expanded rapidly in recent year s and may have been less able to be highly selective in recent years as its numbers have grown. Indeed, as the proportion of fully certified tea chers in Houston grew over the years in our study, and as the proportion of TFA teachers who were certified declined, TFA cohorts went from being better qualified on average to less well-qualif ied on average than other HISD teachers. We found that interpreting the relative influence of TFA teachers on student achievement depends on knowing about the characteristics of the comparis on group of teachers. When compared to less well qualified teachers, TFA teachers appeared to have a neutral or positive effect. When compared to a pool of teachers who were on average better qualifie d, TFA teachers appeared to have a negative effect. Thus, one could anticipate that the relati ve effectiveness of this or any other group of teachers must be evaluated in a specific contex t at a particular point in time, with close understanding of the qualifications and character istics of the comparison groups of teachers employed in that same setting at that point in time. The limitations of teachers without preparation ar e illuminated by this study. It is clear that, across the board, Houston students achieved stronger achievement gains in both reading and mathematics when they were taught by standard cer tified teachers rather than uncertified teachers. Uncertified teachers, both TFA and non-TFA, did particularly poorly with Spanish-speaking students who took the Aprenda tests. This might be a function of the specialized knowledge needed to teach English language learners that may be more consistently acquired in pre-service teacher education programs. These programs may have more time to teach not only the basics of classroom management and lesson planning, but also the strate gies for teaching content to students who have specific language needs. Alternatively certified teachers, although th ey were generally less effective than standard certified teachers, had a strong positive effect on st udent achievement for Spanish-speaking students on the Aprenda in reading. This may be because Houston’s alternative certification program recruits a large number of Hispanic candidates, whose Span ish language skills may help them teach reading in Spanish more effectively than many other teachers. Finally, although students taught by TFA recruits (and other uncertified teachers) were slowed in their academic progress in the first yea r of the recruits’ teaching efforts, one of the accomplishments of Teach for America and HISD was the development of means for enabling recruits to participate in preparation and become certified for teaching in their second or third year of teaching. Houston students did not reap long-ter m benefits from these efforts, however, as the vast majority of the TFA recruits left after their second or third year of teaching. High turnover of beginning teachers is both extremely costly for school districts (Benner, 2000) and counterproductive for students, as teacher effective ness typically increases markedly after about the second year of teaching (Hanushek, Kain, & Rivkin, 1998).


Does Teacher Preparation Matter? 23 Implications for the Recruitment and Preparation of Teachers These findings raise several considerations for districts seeking to design programs and pathways for recruiting and preparing teachers. First, the results suggest that, in the best of circumstances, there are benefits to recruiting fully prepared teachers who can launch their careers at a higher level of effectiveness. However, absent a set of policies that can provide a fully prepared teaching force, the study findings also suggest th at candidates who enter alternative programs like the one offered by HISD can become more effective as they complete the program and become certified over a period of two or three years. We noted that recruits who en ter teaching through alternative programs and pathways may bring different potential strengths with them. We speculated, for example, that TFA teachers’ potentially stronger grounding in mathematics may have contributed to their greater effectiveness in supporting student achievement in mathematics in some years and that HISD alternative program recruits may have been more effective in supporti ng Spanish-speaking students in reading because many are Spanish-speaking teachers. However, thes e benefits did not hold across different tests and areas. This suggests that the personal characteris tics sought by alternative programs are only a starting point for training. Programs should seek to build on the skills candidates bring with them while ensuring that other areas of knowledge and skill are explicitly addressed and developed. For students to benefit from their teachers each year, alternative programs and other nontraditional pathways into teaching should ensure that new recruits-in-trai ning can practice under the close supervision of expert veterans, so that their students—from their very first days in the classroom—have the benefit of a classroom informed by a prepared teacher’s advice and counsel, rather than being put at a disadvantage. Even if such teachers improve their effectiveness with training over several years, the students have only one opportunity to experience second grade, for example, and cannot afford to lose ground in acquiring basic skills even for a single year. And students in high-need schools in cities like Houst on are likely to experience many beginning teachers who are not yet prepared, creating cumulative negative effects on th eir achievement, if they are not offset or supported by teachers with more expertise. Finally, as alternative pathway teachers beco me more expert, students and schools gain benefits only if the teachers stay in the schools that have invested in their training. Cost-effective recruitment programs that increase the share of prepared teachers students ultimately encounter will likely need to recruit candidates with the expect ation of a longer teaching commitment than the two years TFA candidates currently pledge. The North Carolina Teaching Fellows program, for example, recruits high-ability students into teacher education by providing service scholarships that cover the full costs of high quality pre-service training, repaid by at least 4 years of service in public schools. An evaluation found more than 75% still teaching after seven years, and many of the remainder were still in public schools as administrators (Nati onal Commission on Teaching and America’s Future, 1996). A broader challenge for states, school districts, and teacher preparers is how to develop and expand the reach of strong, efficient, and affordable preparation routes that enable teachers to be competent when they enter teaching and that retain teachers as they become more effective. In addition to successful service scholarships like those offered in North Carolina and some other states, the literature includes examples of urban tea cher education programs that have strong records of preparing capable teachers who stay in th e city schools (see for example, Darling-Hammond, Chung, & Frelow, 2002; Darling-Hammond & Ma cDonald, 2000; Koppich, 2000; Snyder, 2000; Zeichner, 2000). Increasing the availability of suc h programs could help stem turnover, as several recent studies have found that teacher attrition is strongly related to the extent of preparation


Education Policy Analysis Archives Vol. 13 No. 42 24 teachers have had upon entry (Henke, Chen, Geis, & Knepper, 2000; National Commission on Teaching and AmericaÂ’s Future, 2003). However, analyses of urban districts that have resolved teacher shortages indicate that additional state and local policies are needed to cr eate the labor market conditions required to hire and retain an adequate supply of prepared teachers. These typically include aggressive outreach and streamlined hiring systems, training subsidies and partnerships with local universities, and recruitment incentives, as well as competitive salaries, reasonable working conditions, and supportive administrators (Darling-Hammond & Syke s, 2003; Murnane, Singer, Willett, Kemple, & Olsen, 1991; National Commission on Teaching and AmericaÂ’s Future, 2003). Thus, improvements in teachers' preparedness are likely to rest on a pol icy strategy that also includes the right mix of incentives for recruiting and retaining qualified teachers.


Does Teacher Preparation Matter? 25 References Ballou, D., & Podgursky, M. (2000). Reforming te acher preparation and licensing: What is the evidence? Teachers College Record 102 (1), pp. 1–27. Benner, A. D. (2000). The cost of teacher turnover Austin, TX: Texas Center for Educational Research. Betts, J.R., Rueben, K.S., & Danenberg, A. (2000). Equal resources, equal outcomes? The distribution of school resources an d student achievement in California San Francisco: Public Policy Institute of California. Darling-Hammond, L. (2000a). Reforming teacher preparation and licensing: Debating the evidence. Teachers College Record, 102 (1), pp. 28–56. Darling-Hammond, L. (2000b). Teacher quality and student achievement: A review of state policy evidence. Educational Policy Analysis Archives, 8 (1). Retrieved October 3, 2005, from Darling-Hammond, L., Chung, R., & Frelow, F. ( 2002). Variation in teacher preparation: How well do different pathways prepare teachers to teach? Journal of Teac her Education, 53 (4): 286–302. Darling-Hammond, L., & MacDonald, M. (2000). Where there is learning there is hope: The preparation of teachers at the Bank Str eet College of Education. In L. DarlingHammond (Ed.), Studies of excellence in teacher educ ation: Preparation at the graduate level (pp. 1–95). Washington, DC: American Association of Colleges for Teacher Education. Darling-Hammond, L. & Sykes, G. (2003). Wa nted: A national teacher supply policy for education: The right way to meet the ‘highly qualified teacher’ challenge. Educational Policy Analysis Archives, 11 (33), retrieved October 3, 2005, from Darling-Hammond, L. & Youngs, P. (2002). Defining “highly qualified teachers:” What does “scientifically-based research” actually tell us? Educational Researcher, 31 (9), 13–25. Decker, P.T., Mayer, D.P., & Glazerman, S. (2004). The Effects of Teach For America on Students: Findings from a National Evaluation Princeton, NJ: Ma thematica Policy Research, Inc. Ferguson, R.F. (1991, Summer). Paying for pu blic education: New evidence on how and why money matters. Harvard Journal on Legislation, 28 (2), 465–498. Fetler, M. (1999). High school staff char acteristics and mathematics test results. Education Policy Analysis Archives, 7 (9), retrieved October 3, 2005, from


Education Policy Analysis Archives Vol. 13 No. 42 26 Finn, C.E. (1999). Foreword. In M. Ka nstoroom & C. E. Finn, Jr. (eds.), Better teachers, better schools (pp. v–vii) Washington, DC: The Thomas B. Fordham Foundation. Fox, J. (1997). Applied regression analysis, line ar models, and related methods Thousand Oaks. CA: Sage Publications. Goe, L. (2002). Legislating equity: The distributi on of emergency permit teachers in California. Educational Policy Analysis Archives 10 (42), retrieved October 3, 2005, from Goldhaber, D.D., & Brewer, D.J. (2000). Does te acher certification matter? High school teacher certification status and student achievement. Educational Evaluation and Policy Analysis, 22 (2), 129–146. Gomez, D. L., and Grobe, R. P. (1990). Three Years of Alternative Ce rtification in Dallas: Where are we? Paper presented at the A nnual Meeting of the American Educational Research Association, Boston, MA. Hanushek, E., Kain, J., & Rivkin, S. (1998). Teachers, schools, and academic achievement. (Working Paper 6691). Cambridge, MA: Na tional Bureau of Ec onomic Research. Hawk, P.P., Coble, C.R., & Swanson, M. (1 985). Certification: It does matter. Journal of Teacher Education, 36 (3), 13–15. Henke, R.R., Chen, X., Geis, S., & Knepper, P. (2000). Progress through the teacher pipeline: 1992–93 college graduates and elementary/ secondary school teac hing as of 1997. NCES 2000–152. Washington, DC: National Center for Education Statistics. International Reading Association (2003). Prepared to make a differen ce: Research evidence on how some of America’s best college pr ograms prepare teachers of reading Newark, NJ: International Read ing Association. Klein, S.P., Hamilton, L.S., McCaffrey, D.F., & Stetcher, B.M. (2000). What do test scores in Texas tell us? Santa Monica: The RAND Corporation. Koppich, J. (2000). Trinity University: Preparing teachers for tomorrow's sc hools. In L. DarlingHammond, (Ed.), Studies of excellence in teacher ed ucation: Preparatio n in a five-year program (pp. 1–48). Washington, DC: American Association of Colleges for Teacher Education. Laczko-Kerr, I., & Berliner, D. (2002). The effe ctiveness of Teach for America and other undercertified teachers on student academic achiev ement: A case of harmful public policy. Educational Policy Analysis Archives, 10 (37), retrieved October 3, 2005, from http://epaa.asu.ed u/epaa/v10n37. Monk, D.H. (1994). Subject area preparation of secondary mathematics an d science te achers and student achievement. Economics of Education Review, 13 (2), 125–145.


Does Teacher Preparation Matter? 27 Murnane, R., Singer, J., Willett, J. Kemple, J., & Ol sen, R. (1991). Who will teach? Policies that matter. Cambridge, MA: Harvard University Press. National Commission on Teaching and America’s Future. (1996). What matters most: Teaching for America’s future. New York: Author. National Commission on Teaching and America’s Future. (2003). No dream denied. Washington, DC: Author. National Reading Panel (2000). Teaching children to read: An evidence-based assessment of the scientific research literature on reading and its implications for reading instruction. Washington, DC: National Institute of Child Health and Human Development. Raudenbush, S. W. & Bryk, A. S. (2002). Hierarchical linear models: Applications and data analysis methods (2nd Ed.). Thousand Oaks, CA: Sage Publications. Raymond, M. & Fletcher, S. H. (2002). The Teach for America evaluation. Education Next, 2 (1): 62–68. Raymond, M., Fletcher, S.H., & Luque, J. (2001). Teach for America: An evaluation of teacher differences and student outc omes in Houston, Texas. Stanford, CA: The Hoover Institution, Center for Rese arch on Education Outcomes. Shields, P.M., Esch, C.E., Humphrey, D.C., Wech sler, M.E., Chang-Ross, C.M., Gallagher, H.A., Guha, R., Tiffany-Morales, J.D., & Woodworth, K.R. (2003). The status of the teaching profession 2003 Santa Cruz, CA: The Center for the Future of Teaching and Learning. Snyder, J. (2000). Knowing children—understa nding teaching: The developmental teacher education program at the University of Ca lifornia, Berkeley. In L. Darling-Hammond (Ed.), Studies of excellence in teacher educat ion: Preparation at the graduate level (pp. 97– 172). Washington, D.C.: American Associat ion of Colleges for Teacher Education. Strauss, R. P. and Sawyer, E.A. (1986). Some new evidence on teacher and student competencies. Economics of Education Review, 5 (1): 41–48. U.S. Department of Education (2002). The Secretary’s report on teacher quality. Washington, DC: U.S. Department of Education. Wenglinsky, H. (2000). How teaching matters: Bringing the classroom back into discussions of teacher quality. Princeton, NJ: Educatio nal Testing Service. Wilson, S.M., Floden, R., & Ferrini-Mundy, J. (2001). Teacher preparation research: Current knowledge, gaps, and recommendations. A research report pr epared for the U.S. Department of Education. Seattle: Center for the Stud y of Teaching and Policy, University of Washington. Zeichner, K. M. (2000). Ability-based teacher education: Elementary teacher education at Alverno College. In L. Darling-Hammond, (Ed.), Studies of excellence in teacher


Education Policy Analysis Archives Vol. 13 No. 42 28 education: Preparation in the undergraduate years (pp. 1–66). Washington, D.C.: American Association of Colleges for Te acher Education Publications.


Does Teacher Preparation Matter? 29 About the Authors Linda Darling-Hammond Deborah J. Holtzman Su Jin Gatlin Julian Vasquez Heilig Stanford University Email: Linda Darling-Hammond is Charles E. Ducommun Professor of Education at Stanford University. Am ong her many publications on issues of teacher quali ty, school reform, and educational equity are The Right to Learn: A Blueprint for Creating Schools that Work and Teaching as the Learning Profession : A Handbook of Policy and Practice Deborah J. Holtzman is a PhD candidate in the Admi nistration and Policy Analysis program at the Stanford University School of Education. She is also a Research Analyst at the American Institutes for Research. Her current research interests incl ude accountability and alignment among instruction, standards, and assessment. Su Jin Gatlin is a PhD candidate in Administrati on and Policy Analysis at Stanford University's School of Education. She is also completing a Mas ter's in Economics at Stanford and holds a BA in Statistics from UC Berkeley. He r current research interests include the role of wealth on postsecondary attendan ce and school finance reform. Julian Vasquez Heilig is a Ph.D. candidate in Administration and Policy Analysis at Stanford University. His rese arch focuses on accountabilit y policy and urban education.


Education Policy Analysis Archives Vol. 13 No. 42 30 APPENDIX A Descriptive Statistics Table A-1 Univariate Statistics for Vari ables in the Re gression Models1 TLI / TAAS (1996–97—2001–02) SAT-9 (1999–2000—2001–02) Aprenda (1999–2000—2001–02) Mean S.Dev. Mean S. Dev. Mean S. Dev. Test Score Math 81.31 10.45 55.60 19.13 58.52 16.53 Test Score Reading 85.46 12.34 48.83 19.73 56.06 16.53 Previous Year test score Math 78.07 12.00 55.85 19.80 57.02 16.03 Previous Year test score Reading 82.56 12.59 49.07 19.33 56.69 15.48 Free/ Reduced Price Lunch (student) 0.69 0.46 0.72 0.45 0.98 0.15 American Indian (student) 0.001 0.03 0.001 0.03 0.000 0.000 Asian/Pacific Islander (student) 0.03 0.18 0.036 0.19 0.000 0.02 African American (student) 0.43 0.50 0.42 0.49 0.001 0.03 Hispanic (student) 0.38 0.49 0.41 0.41 0.99 0.05 Limited English Proficient (stu dent) 0.16 0.37 0.24 0.43 0.95 0.21 Total years of experience (tea cher) 12.54 10.24 12.14 10.46 7.15 7.43 Masters or Doctoral degree (teacher) 0.29 0.46 0.27 0.45 0.15 0.36 Classroom Number of Students (in grades 3-5) 25.62 4.13 26.18 4.37 24.77 4.38 Class average previous year test score math 77.60 6.95 55.69 11.87 57.42 7.27 Class average previous year test score reading 82.03 7.28 48.94 12.19 56.99 7.01 Percent African American students in school 37.69 33.23 36.82 33.07 12.93 16.48 Percent Hispanic students in sc hool 46.61 32.46 48.45 32.55 81.42 18.84 Percent free/reduced price lunch students in school 74.85 43.32 75.49 42.97 95.66 20.35 Certification date unknown (tea cher) 0.113 0.32 0.054 0.23 0.093 0.290 Uncertified 0.206 0.40 0.224 0.42 0.261 0.439 Alternatively certified 0.003 0.06 0.005 0.07 0.013 0.111


Does Teacher Preparation Matter? 31 TLI / TAAS (1996–97—2001–02) SAT-9 (1999–2000—2001–02) Aprenda (1999–2000—2001–02) Mean S.Dev. Mean S. Dev. Mean S. Dev. Emergency / temporary certified 0.052 0.22 0.030 0.17 0.039 0.194 Certified Out-of-Field 0.009 0.09 0.014 0.12 0.006 0.080 Certified no-test 0.010 0.10 0.006 0.08 0.018 0.134 Certification missing 0.051 0.22 0.028 0.17 0.052 0.222 TFA Status 0.021 0.14 0.023 0.15 0.015 0.120 TFA teacher, uncertified 0.010 0.09 0.013 0.11 0.008 0.089 TFA teacher, standard certified 0.011 0.11 0.010 0.10 0.007 0.081 Non-TFA teacher, uncertified 0.197 0.40 0.211 0.41 0.255 0.436 Non-TFA teacher, nonstandard certified 0.116 0.32 0.068 0.25 0.119 0.324 1This table reports statistics for records in the pooled-year re gressions. Except where specific to reading scores, the statisti cs report the means and standard deviations for data used in the math analyses for each test. Although there were small differences in the sample s izes for reading and math on each test, the statistics are identical to the one-tenths place.


Education Policy Analysis Archives Vol. 13 No. 42 32 Table A-2 Certification Status of 4th and 5th Grade Teachers, by Year 1996-97* 1997-98* 1998-99 1999-00 2000-01 2001-02 Certification Status NonTFA TFA NonTFA TFA NonTFA TFA NonTFA TFA NonTFA TFA NonTFA TFA Standard (N) 56.5% (1028) 65.2% (15) 61.6% (1089) 68.6% (24) 65.4% (1041) 73.1% (19) 67.8% (1181) 48.3% (14) 68.7% (1216) 45.7% (16) 64.8% (1137) 45.2% (19) Alternative (N) 0.2% (4) 0.0% (0) 0.3% (5) 0.0% (0) 0.3% (5) 3.8% (1) 0.3% (5) 0.0% (0) 0.6% (11) 8.6% (3) 0.7% (12) 4.8% (2) Emergency/ Temporary (N) 9.5% (172) 0.0% (0) 8.7% (154) 0.0% (0) 5.8% (92) 0.0% (0) 3.9% (68) 0.0% (0) 2.7% (48) 0.0% (0) 2.0% (35) 0.0% (0) Certified Outof-field (N) 0.1% (2) 0.0% (0) 0.2% (3) 0.0% (0) 0.3% (4) 0.0% (0) 0.3% (5) 0.0% (0) 1.0% (17) 0.0% (0) 2.2% (38) 0.0% (0) Certified, No test (N) 2.3% (42) 0.0% (0) 1.2% (22) 0.0% (0) 0.6% (9) 0.0% (0) 0.9% (16) 0.0% (0) 0.8% (15) 0.0% (0) 1.0% (18) 0.0% (0) Not yet certified (N) 20.4% (370) 34.8% (8) 20.1% (355) 31.4% (11) 23.0% (366) 23.1% (6) 23.2% (404) 51.7% (15) 22.1% (391) 45.7% (16) 25.8% (453) 50.0% (21) Certification missing (N) 11.0% (200) 0.0% (0) 7.9% (139) 0.0% (0) 4.7% (74) 0.0% (0) 3.6% (62) 0.0% (0) 4.1% (72) 0.0% (0) 3.5% (61) 0.0% (0) In these years, the HISD data set included a number of candid ates with certification codes but not certification dates (16% o f the total in 199697 and 13% in 1997-98). They are listed in this table in the ca tegory indicated by their certification code for each year that they appear in the data set. We are cautious in drawing inferences for these two years about when the certification status went into effect. Note: Includes all teachers who taught any 4th or 5th grade student


Does Teacher Preparation Matter? 33 Table A-3 Student Sample Sizes, By Test and Year Year TLI Math TLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading 1996-97 16,635 16,265 — — — — 1997-98 16,738 16,342 — — — — 1998-99 16,954 16,616 — — — — 1999-00 18,067 17,550 19,880 19,934 3,854 3,852 2000-01 18,205 17,723 20,006 20,039 3,820 3,819 2001-02 18,912 18,626 20,602 20,634 3,763 3,765


Education Policy Analysis Archives Vol. 13 No. 42 34 APPENDIX B Ordinary Least Squares Regression Estimates Table B-1 Regression Coefficients, TFA Status and Student Achievement, Houston ISD, Grades 4–5 (pooled years) Variable TLI MathTLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading Constant 30.35*** (77.87) 31.67*** (66.24) 15.46*** (27.67) 9.96*** (18.57) 24.46*** (6.37) 7.33~ (1.92) Previous year test score 0.498*** (201.90) 0.526*** (184.37) 0.683*** (223.70) 0.742*** (240.41) 0.670*** (81.37) 0.706*** (83.31) Free/reduced price lunch status -0.922*** (-13.77) -1.41*** (-17.19) -1.70*** (-12.36) -1.68*** (-12.76) 0.677 (0.856) 0.991 (1.26) American Indian 0.161 (0.189) 0.135 (0.129) 1.71 (0.963) -0.278 (-0.170) — — Asian/Pacific Islander 0.678*** (4.50) 0.541** (2.94) 2.32*** (7.81) 0.616* (2.17) 9.55 (1.34) 9.84 (1.39) African American -1.66*** (-17.19) -2.23*** (-18.94) -3.03*** (-15.41) -2.49*** (-13.17) -3.17 (-0.592) 11.06~ (1.82) Hispanic -0.665*** (-6.98) -1.32*** (-11.32) -1.22*** (-6.25) -1.86*** (9.95) -0.866 (-0.263) 4.45 (1.36) Limited English Proficient 1.58*** (20.70) 0.664*** (7.09) 0.884*** (6.34) 0.872*** (6.51) 2.08*** (3.71) 1.36* (2.44) Total teaching experience -0.012*** (-4.45) 0.002 (0.508) 0.035*** (6.90) 0.054*** (11.24) 0.107*** (6.22) 0.024 (1.39) Masters degree or higher -0.224*** (-3.87) -0.097 (-1.37) -0.285* (-2.47) -0.356** (-3.22) -0.524 (-1.46) 0.236 (0.663) Classroom number of students 0.148*** (24.94) 0.019** (2.67) -0.029** (-2.68) 0.020~ (1.87) 0.144*** (5.22) 0.197*** (7.19) Class average previous year test score0.117*** (25.86) 0.150*** (28.37) 0.100*** (17.17) 0.123*** (21.20) -0.049** (-2.66) -0.061** (-3.22)


Does Teacher Preparation Matter? 35 Variable TLI MathTLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading % African American students in school 0.010*** (4.41) -0.003 (-1.15) 0.003 (0.710) -0.022*** (-4.98) -0.137*** (-6.36) 0.015 (0.492) % Hispanic students in schools 0.013*** (5.42) -0.002 (-0.627) -0.010* (-2.02) -0.030*** (-6.54) -0.125*** (-6.21) -0.003 (-0.154) % free/reduced price lunch students in school -0.003** (-2.74) 0.001 (0.799) -0.002 (-0.698) 0.005** (2.63) 0.048*** (6.43) 0.005 (0.699) TFA teacher status 0.689*** (3.98) -0.039 (-0.184) -0.882** (-2.74) -0.642* (-2.08) -2.87** (-2.88) -2.58** (-2.61) R2 .43 .39 .62 .68 .42 .43 N 105,511 103,122 60,488 60,607 11,437 11,436 T-values are in parentheses. ~ p <.10; *p<.05; **p<.01; ***p<.001


Education Policy Analysis Archives Vol. 13 No. 42 36 Table B-2 Regression Coefficients, Certification Status and Student Achievement, Ho uston ISD, Grades 4–5 (pooled years) Variable TLI Math TLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading Constant 30.98*** (79.19) 32.11*** (66.60) 15.59*** (27.94) 10.05*** (18.70) 24.02*** (6.26) 7.82* (2.05) Previous year test score 0.498*** (202.28) 0.527*** (184.45) 0.683*** (223.85) 0.742*** (240.49) 0.670*** (81.61) 0.706*** (83.54) Free/reduced price lunch status -0.912*** (-13.63) -1.41*** (-17.16) -1.69*** (-12.29) -1.68*** (-12.73) 0.656 (0.831) 0.888 (1.14) American Indian 0.210 (0.247) 0.130 (0.125) 1.87 (1.05) -0.134 (-0.079) — — Asian/Pacific Islander 0.703*** (4.67) 0.553** (3.01) 2.35*** (7.92) 0.638* (2.24) 9.60 (1.35) 10.36 (1.47) African American -1.67*** (-17.31) -2.23*** (-18.98) -3.03*** (-15.38) -2.47*** (-13.11) -3.27 (-0.613) 10.87~ (1.80) Hispanic -0.657*** (-6.91) -1.32*** (-11.32) -1.22*** (-6.27) -1.86*** (9.96) -0.358 (-0.109) 4.81 (1.48) Limited English Proficient 1.50*** (19.52) 0.631*** (6.72) 0.902*** (6.47) 0.873*** (6.52) 1.84** (3.26) 1.05~ (1.88) Total teaching experience -0.025*** (-9.23) -0.008* (-2.23) 0.031*** (5.76) 0.050*** (9.72) 0.082*** (4.03) 0.030 (1.61) Masters degree or higher -0.169** (-2.88) -0.077 (-1.08) -0.252* (-2.18) -0.329** (-2.97) -0.393 (-1.05) 0.369 (0.991) Classroom number of students 0.147*** (24.86) 0.020** (2.76) -0.028** (-2.52) 0.022* (2.06) 0.145*** (5.24) 0.194*** (7.06) Class average previous year test score0.113*** (25.10) 0.147*** (27.83) 0.100*** (17.18) 0.122*** (21.12) -0.041* (-2.21) -0.057** (-3.00) % African American students in school 0.011*** (4.63) -0.003 (-0.871) 0.003 (0.747) -0.022*** (-4.95) -0.132*** (-6.04) 0.003 (0.154) % Hispanic students in schools 0.014*** (5.65) -0.001 (-0.424) -0.010* (-2.12) -0.030*** (-6.51) -0.126*** (-6.22) -0.012 (-0.614) % free/reduced price lunch students in school -0.003* (-2.43) 0.001 (0.725) -0.002 (-0.768) 0.005* (2.55) 0.050*** (6.57) 0.006 (0.758)


Does Teacher Preparation Matter? 37 Variable TLI Math TLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading Uncertified -0.525*** (-8.03) -0.580*** (-7.23) -0.414** (-3.30) -0.516*** (-4.31) -1.41*** (-4.61) -0.066 (-0.216) Alternatively certified -0.897* (-2.02) -0.818 (-1.49) -2.31** (-3.29) -1.40* (-2.09) -0.491 (-0.454) 3.13** (2.91) Emergency/temporary certified -0.701*** (-3.85) -0.690** (-3.07) -0.636~ (-1.68) 0.780* (2.16) -1.40 (-1.15) -0.754 (-0.619) Certified out-of-field 0.667* (2.52) 0.902** (2.77) -1.80*** (-4.36) 0.216 (0.548) -3.96** (-2.64) 3.64* (2.45) Certified, no test -0.187 (-0.655) -0.655~ (-1.87) -4.49*** (-7.06) -2.34*** (-3.83) -3.52*** (-3.66) -4.76*** (-5.01) Certification code missing 0.113 (0.549) -0.642* (-2.53) -2.26*** (-4.63) 0.121 (0.260) -4.78*** (-3.84) -4.37*** (-3.52) Certification date unknown -1.09*** (-6.17) 0.043 (0.199) 1.65*** (4.07) 0.152 (0.393) 4.43*** (3.82) 4.66*** (4.03) R2 .43 .39 .62 .68 .42 .43 N 105,511 103,122 60,488 60,607 11,437 11,436 T-values are in parentheses. ~ p <.10; *p<.05; **p<.01; ***p<.001


Education Policy Analysis Archives Vol. 13 No. 42 38 Table B-3 Regression Coefficients, TFA Status, Certif ication Status, and Student Achievement, Houston ISD, Grad es 4–5 (pooled years) Variable TLI MathTLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading Constant 30.91*** (77.11) 32.12*** (66.74) 15.58*** (27.93) 10.09*** (18.78) 24.79*** (6.46) 7.39~ (1.94) Previous year test score 0.498*** (201.26) 0.527*** (184.46) 0.684*** (223.77) 0.743*** (240.46) 0.670*** (81.52) 0.706*** (83.42) Free/reduced price lunch status -0.917*** (-13.71) -1.41*** (-17.16) -1.69*** (-12.32) -1.68*** (-12.70) 0.703 (0.891) 0.981 (1.25) American Indian 0.186 (0.218) 0.115 (0.110) 1.64 (0.922) -0.332 (-0.197) — — Asian/Pacific Islander 0.702*** (4.66) 0.553** (3.01) 2.33*** (7.83) 0.630* (2.21) 9.55 (1.35) 10.21 (1.45) African American -1.67*** (-17.36) -2.23*** (-18.99) -3.03*** (-15.37) -2.48*** (-13.14) -3.15 (-0.590) 11.12~ (1.83) Hispanic -0.657*** (-6.91) -1.32*** (-11.32) -1.21*** (-6.24) -1.86*** (9.97) -0.477 (-0.145) 4.71 (1.44) Limited English Proficient 1.51*** (19.67) 0.639*** (6.81) 0.883*** (6.33) 0.865*** (6.46) 1.89** (3.37) 1.33* (2.39) Total teaching experience -0.022*** (-7.88) -0.007* (-2.07) 0.029*** (5.34) 0.048*** (9.42) 0.077*** (4.03) 0.027 (1.43) Masters degree or higher -0.169** (-2.93) -0.070 (-0.992) -0.296* (-2.56) -0.358** (-3.24) -0.418 (-1.15) 0.303 (0.838) Classroom number of students 0.147*** (24.81) 0.020** (2.71) -0.029** (-2.61) 0.021* (1.99) 0.138*** (5.00) 0.194*** (7.07) Class average previous year test score 0.114*** (25.33) 0.147*** (27.85) 0.099*** (17.05) 0.122*** (21.04) -0.048** (-2.61) -0.058** (-3.02) % African American students in school 0.010*** (4.39) -0.003 (-0.921) 0.004 (0.913) -0.022*** (-4.84) -0.136*** (-6.27) 0.007 (0.319) % Hispanic students in schools 0.013*** (5.22) -0.001 (-0.485) -0.008~ (-1.78) -0.029*** (-6.32) -0.125*** (-6.22) -0.010 (-0.499) % free/reduced price lunch students in school -0.002* (-2.22) 0.001 (0.767) -0.002 (-0.889) 0.005* (2.46) 0.049*** (6.55) 0.006 (0.809)


Does Teacher Preparation Matter? 39 Variable TLI MathTLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading TFA teacher, uncertified -0.288 (-1.14) -1.22*** (-3.93) -1.89*** (-4.41) -1.09** (-2.67) -4.06** (-3.01) -5.09*** (-3.81) TFA teacher, standard certified 1.18*** (4.93) 0.437 (1.49) -0.008 (0.017) -0.458 (-0.994) -2.55~ (-1.73) 0.839 (0.572) Non-TFA teacher, unce rtified -0.488*** (-7.36) -0.550*** (-6.76) -0.341** (-2.68) -0.519*** (-4.25) -1.33*** (-4.30) -0.014 (-0.045) Non-TFA teacher, nonstandard certified -0.284 (-1.63) -0.605** (-2.81) -1.54*** (-4.60) -0.051 (-0.159) -2.45*** (-3.53) -1.26~ (-1.83) R2 .43 .39 .62 .68 .42 .43 N 105,511 103,122 60,488 60,607 11,437 11,436 T-values are in parentheses. ~ p <.10; *p<.05; **p<.01; ***p<.001


Education Policy Analysis Archives Vol. 13 No. 42 40 APPENDIX C Analysis with Hierarch ical Linear Modeling This appendix describes a preliminary analysis of the data that was done using Hierarchical Linear Modeling (HLM). This analysis paralle led the OLS regression analysis for Teacher Certification and TFA Status (see Table7 of the ma in paper) in every way except that the HLM analysis took into account the nesting of students within classrooms and classrooms within schools. The variables used were identical, as were the records included. Rationale for the HLM Analysis We originally used OLS analysis in order to recreate the analyses conducted in the CREDO study using Houston’s data. However, as undertaken here, the HLM analysis had two primary advantages over the OLS analysis. First, the OLS an alysis treated all students as independent of one another when in fact students were groups within classrooms as well as within schools. Similarly, the OLS analysis did not take into account the grou ping of teachers within schools. As such, the standard errors from the OLS results could be es timated to be smaller than appropriate, possibly inflating significance results. The HLM analysis atte mpted to remedy this problem by taking into account the nesting of students (level 1) within cla ssrooms/teachers (level 2) within schools (level 3). Second, the HLM analysis allowed for the modeling of within-school relationships between the teacher variables and student achievement outcomes (that is, the relationships net of any school membership effects). This was accomplished by cen tering the teacher/classroom (level 2) variables around their school (level 3) means. (See Raudenbush & Bryk, 2002, pp. 135-139). Despite its advantages, the HLM analysis reported here has some important limitations. In particular, this analysis (like the OLS analysis) did not take into account the longitudinal nature of the data. Each student was represented by a distinct and separate record for each year he or she was in the data base; this was also true of teachers an d schools. Just as with th e OLS analysis, a single student may have been included as a fourth grader and, again, as a fifth grader; such a student was, in effect, treated as two independent students. Th e same was true for teachers, many of whom were in the data base for multiple years but were treated independently for each classroom-year, and schools. Ideally, the data would be modeled as crossclassified random effects of students crossing teachers nested within schools over time; however, th is is a complex specification that could not be undertaken for this paper. This approach may be pursued in future work. Method The HLM analysis used the exact same data and variables as were used for the OLS analysis. However, the HLM analysis employed a three-level technique where level 1 was students, level 2 was teachers/classrooms, and level 3 was schools. The level-1 predictors were the student control variables: previous-year test score, free/reduced price lunch status, race/ethnicity and LEP status. The level-2 predictors included the four variable s of primary interest—(1) TFA teacher, uncertified or nonstandard certified; (2) TFA teacher, standard certified; (3) non-TFA teacher, uncertified; and (4) non-TFA teacher, nonstandard certified—with nonTFA standard-certified teachers serving as the reference group. Also included at level 2 were the teacher/classroom-level controls: years of


Does Teacher Preparation Matter? 41 teaching experience, degree level (masters/doctoral vs bachelors or below), an indicator for missing certification date, classroom number of students, and class average previous year test score. The level-3 predictors were the schoolwide percentage s of free/reduced price lunch students, African American students, and Hispanic students. Models were built up from level 1, with predictors added in groups. For each different outcome variable (the six test measures), a series of six models were constructed. The first (Model A) was fully unconditional, with no predictors thereby allowing computation of the variance explained at each of the three levels. The second model (Model B) added the student-level previousyear achievement variable, grand-mean centered, at level 1. Model C added all of the other studentlevel predictors, grand-mean centered. Model D added at level 2 all of the teacher/classroom level predictors, group-mean centered, except the cl assroom previous achievement average. Model E added in the classroom previous achievement averag e, group-mean centered (and at the same time changed the centering on the level-1 previous achievement variable to group-mean centering). The final model (Model F) added at level 3 the school-level predictors, grand-mean centered. The models included random effects only on the intercepts (which, due to the centering, represent adjusted class/school achievement means); all slope effects were set as fixed. Accordingly, the level-2 and level-3 variables were used as predictors only in the intercept equations. The equations for Model F are as follows ( i indexes students, j indexes teachers/classrooms, and k indexes schools): Level 1: Yijk = 0jk + 1jk(PREV ACHijk – PREV ACH.jk) + 2jk(FRPLijk – FRPL…) + 3jk(AMINDijk – AMIND…) + 4jk(ASIANijk – ASIAN…) + 5jk(BLACKijk – BLACK…) + 6jk(HISPANICijk – HISPANIC…) + 7jk(LEPijk – LEP…) + eijk Level 2: 0jk = 00k + 01k(TFANONSTDjk – TFANONSTD.k) + 02k(TFASTDjk – TFASTD.k) + 03k(NONTFAUNCERTjk – NONTFAUNCERT.k) + 04k(NONTFAOTHCERTjk – NONTFAOTHCERT.k) + 05k(EXPERjk – EXPER.k) + 06k(MADOCjk – MADOC.k) + 07k(NOCERTDATEjk – NOCERTDATE.k) + 08k(CLSNUMSTUjk – CLSNUMSTU.k) + 09k(CLSAVGPREVACHjk – CLSAVGPREVACH.k) + r0jk 1jk = 10k 2jk = 20k … 7jk = 70k Level 3: 00k = 000 + 001(BLACKPCTk – BLACKPCT.) + 002(HISPPCTk – HISPPCT.) + 003(FRPLPCTk – FRPLPCT.) + u00k 01k = 010 02k = 020 … 09k = 090 10k = 100


Education Policy Analysis Archives Vol. 13 No. 42 42 20k = 200 Â… 70k = 700 Results Table C-1 shows the Model F results (fixed e ffects and variance components) from all six outcome measures. Tables C-2 and C-3 show the re sults from Models A-F for TAAS/TLI math and TAAS/TLI reading, mainly as an illustration of the full model-building process; results from the full process for the other four outcome measures are available upon request. The TFA/Certification status results are gene rally similar to those obtained by the OLS analyses, although, as to be expected, significan ce levels tend to be lower. Students taught by uncertified TFA teachers made significantly le ss progress on three of the six tests (TAAS/TLI reading, SAT-9 reading, and Aprenda math) than the students of non-TFA standard-certified teachers; TFA coefficients on the ot her three tests were also negative but not significant. Thus, the HLM results support the OLS finding that in no instance do the students of uncertified TFA teachers perform better than the studen ts of standard-certified teachers. Non-TFA uncertified teachers had significan t negative effects, relative to non-TFA standard-certified teachers, on four of the six tests, and non-significant effects on the other two. Students of certified TFA teachers performed compar ably to students of other certified teachers on all six tests (no statistically significant differences). Again, these results are similar to the OLS results.


Does Teacher Preparation Matter? 43 Table C-1 HLM Parameter Estimates, Teacher Certification, TFA Status, and Student Achievement Gains, Houston ISD, Grades 4–5 (pooled years) Variables TLI Math TLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading Fixed Effects, Adjusted Achievement Means Intercept 80.35*** (608.77) 84.13*** (590.63) 53.40*** (217.33) 45.97*** (194.79) 57.94*** (134.64) 55.69*** (151.96) Student-level variablesa Previous year test score 0.500*** (94.55) 0.528*** (94.53) 0.686*** (161.87) 0.744*** (166.59) 0.666*** (73.73) 0.701*** (68.25) Free/reduced price lunch status -0.709*** (-11.49) -1.14*** (-15.17) -1.05*** -8.39 -1.26*** (-9.68) 0.347 (0.493) 0.583 (0.845) American Indian 0.110 (0.239) -0.37 (-0.497) 1.69 (1.28) -0.550 (-0.354) N/A N/A Asian/Pacific Islander 0.810*** (8.35) 0.379** (2.84) 2.26*** (8.06) 0.636* (2.062) 9.958 (1.132) 10.93** (2.68) African American -1.62*** (-16.44) -2.14*** (-19.33) -2.80*** (-14.05) -2.42*** (-12.74) -4.760 (-0.897) 8.57 (1.34) Hispanic -0.536*** (-6.27) -1.23*** (-11.37) -1.23*** (-6.31) -1.75*** (-9.27) -0.976 (-0.192) 6.26** (2.73) Limited English Proficient 0.804*** (11.00) 0.620*** (6.18) 1.07*** (7.07) 0.883*** (6.19) 1.42* (2.08) 1.73** (2.70) Classroom-level variablesb TFA teacher, uncertified or nonstandard certified -0.445 (-0.768) -1.34* (-2.20) -1.52 (-1.57) -1.54* (-2.41) -6.75** (-2.69) -2.60 (-0.927) TFA teacher, standard certified 0.901 (1.54) 0.974 (1.31) 0.093 (0.074) 0.497 (0.493) -3.03 (-0.646) -2.88 (-1.07) Non-TFA teacher, uncertified -0.574*** (-3.81) -0.583** (-3.58) -0.552~ (-1.94) -0.540* (-2.06) -0.566 (-0.613) 0.685 (0.813) Non-TFA teacher, nonstandard certified -0.387 (-0.797) -0.587 (-1.11) -1.82* (-2.00) -0.567 (-0.758) 0.968 (0.555) -2.04 (-0.796) Total teaching experience -0.021** (-3.01) -0.000 (-0.040) 0.024~ (1.87) 0.044*** (3.95) 0.022 (0.443) 0.003 (0.060) Masters degree or higher -0.022 (-0.177) 0.065 (0.461) 0.014 (0.060) -0.022 (-0.102) -0.483 (-0.482) 1.50~ (1.66) Certification Date unknown -0.279 (-0.555) 0.165 (0.297) 1.85~ (1.79) 0.967 (1.13) 0.429 (0.247) 4.74~ (1.82) Classroom number of students 0.181*** (9.33) 0.013 (0.643) 0.013 (0.373) 0.067* (2.19) -0.157 (-1.46) 0.293** (2.99)


Education Policy Analysis Archives Vol. 13 No. 42 44 Variables TLI Math TLI Reading SAT-9 Math SAT-9 Reading Aprenda Math Aprenda Reading Class average previous year test score 0.584*** (44.71) 0.627*** (47.61) 0.787*** (62.52) 0.869*** (78.23) 0.556*** (9.84) 0.501*** (9.56) School-level variablesc % African American students in school -0.065*** (-7.05) -0.082*** (-8.61) -0.213*** (217.33) -0.262*** (194.79) -0.111 (-1.46) 0.014 (0.249) % Hispanic students in school -0.056*** (-5.70) -0.089*** (-8.77) -0.214*** (-9.30) -0.282*** (-12.917) -0.140* (-2.01) -0.042 (-0.812) % free/reduced price lunch students in school -0.004 (-0.869) -0.006 (-1.15) -0.025* (-2.11) -0.034** (-3.03) 0.029 (1.06) 0.008 (0.448) Variance Components Level 1 (student) 43.44 72.13 108.40 104.88 110.56 127.96 Level 2 (classroom) 13.37 14.00 22.35 16.57 30.82 34.64 Level 3 (school) 15.08 17.37 27.41 25.94 34.74 16.77 Level 1 N 105511 103122604886060711437 11436 Level 2 N 6530 651932873287763 762 Level 3 N 1105 1105559559310 310 Coefficients (and Robust T) and Variance Compon ents from Final Models (Modeled adjusted mean achievement only; all slope coefficients set as fixed) ~p<.10, p<.05, ** p<.01, ***p<.001 a All student-level variables grand-me an centered except the previous year test score, which was group-mean centered. b All classroom/teacher-level va riables group-mean centered. c All school-level variables grand-mean centered.


Does Teacher Preparation Matter? 45 Table C-2 HLM Parameter Estimates, Teacher Certificatio n, TFA Status, and Student Achievement Gains in TLI Math only, Houston ISD, Grad es 4–5, by model (pooled years) Variables Model A Model B Mode l C Model D Model E Model F Fixed Effects, Adjusted Achievement Means Intercept 80.52*** (571.35) 80.99*** (764.46) 81.02*** (790.99) 81.00*** (789.19) 80.38*** (584.21) 80.35*** (608.77) Student-level variablesa Previous year test score 0.515*** (97.20) 0.505*** (96.70) 0.505*** (96.49) 0.499*** (94.61) 0.500*** (94.55) Free/reduced price lunch status -0.727*** (-11.95) -0.731*** (-12.03) -0.749*** (-12.20) -0.709*** (-11.49) American Indian 0.076 (0.164) 0.079 (0.171) 0.070 (0.152) 0.110 (0.239) Asian/Pacific Islander 0.784*** (8.18) 0.790*** (8.24) 0.800*** (8.22) 0.810*** (8.35) African American -1.64*** (-17.09) -1.65*** (-17.18) -1.70*** (-17.49) -1.62*** (-16.44) Hispanic -0.544*** (-6.50) -0.550*** (-6.58) -0.579*** (-6.84) -0.536*** (-6.27) Limited English Proficient 0.822*** (11.32) 0.813*** (11.22) 0.798*** (10.90) 0.804*** (11.00) Classroom-level variablesb TFA teacher, uncertified or nonstandard certified -0.470 (-0.876) -0.447 (-0.772) -0.445 (-0.768) TFA teacher, standard certified 0.992~ (1.69) 0.897 (1.53) 0.901 (1.54) Non-TFA teacher, uncertified -0.669*** (-4.54) -0.574*** (-3.81) -0.574*** (-3.81) Non-TFA teacher, nonstandard certified -0.457 (-0.938) -0.388 (-0.798) -0.387 (-0.797) Total teaching experience -0.015* (-2.15) -0.021** (-3.02) -0.021** (-3.01) Masters degree or higher -0.106 (-0.847) -0.023 (-0.184) -0.022 (-0.177) Certification Date unknown -0.265 (-0.525) -0.276 (-0.549) -0.279 (-0.555) Classroom number of students 0.187*** (9.59) 0.182*** (9.34) 0.181*** (9.33)


Education Policy Analysis Archives Vol. 13 No. 42 46 Variables Model A Model B Mode l C Model D Model E Model F Class average previous year test score 0.583*** (44.67) 0.584*** (44.71) School-level variablesc % African American students in school -0.065*** (-7.05) % Hispanic students in school -0.056*** (-5.70) % free/reduced price lunch students in school -0.004 (-0.869) Variance Components Level 1 (student) 71.05 43.86 43.43 43.43 43.44 43.44 Level 2 (classroom) 24.44 13.98 13.79 13.26 13.34 13.37 Level 3 (school) 15.91 9.48 8.64 8.76 16.95 15.08 Coefficients (and Robust T) and Variance Compon ents from Final Models (Modeled adjusted mean achievement only; all slope coefficients set as fixed) ~p<.10, p<.05, ** p<.01, ***p<.001 Reference Group for TFA/certification variables is Non-TFA teacher, standard certified Reference Group for student ethnic ity variables is White students a All student-level variables grand-mean centered, excep t, in Models E and F only, the previous year test score, which was group-mean centered in these two models. b All classroom/teacher-level va riables group-mean centered. c All school-level variables grand-mean centered.


Does Teacher Preparation Matter? 47 Table C-3 HLM Parameter Estimates, Teacher Certificatio n, TFA Status, and Student Achievement Gains in TLI Reading only, Houston ISD, Gr ades 4–5, by model (pooled years) Variables Model A Model B Mode l C Model D Model E Model F Fixed Effects, Adjusted Achievement Means Intercept 84.41*** (539.01) 85.08*** (771.44) 85.18*** (817.49) 85.17*** (816.57) 84.19*** (552.47) 84.13*** (590.63) Student-level variablesa Previous year test score .547*** (97.62) .537*** (97.47) .537*** (97.31) .527*** (94.63) .528*** (94.53) Free/reduced price lunch status -1.20*** (-16.12) -1.20*** (-16.12) -1.22*** (-16.20) -1.14*** (-15.17) American Indian -.412 (-.549) -.419 (-.559) -.443 (-.590) -.37 (-.497) Asian/Pacific Islander .369** (2.77) .369** (2.78) .357** (2.66) .379** (2.84) African American -2.21*** (-20.84) -2.21*** (-20.84) -2.24*** (-20.62) -2.14*** (-19.33) Hispanic -1.29*** (-12.30) -1.29*** (-12.29) -1.34*** (-12.55) -1.23*** (-11.37) Limited English Proficient .589*** (5.89) .583*** (5.84) .612*** (6.10) .620*** (6.18) Classroom-level variablesb TFA teacher, uncertified or nonstandard certified -1.52** (-2.70) -1.35* (-2.21) -1.34* (-2.20) TFA teacher, standard certified .984 (1.31) .959 (1.29) .974 (1.31) Non-TFA teacher, uncertified -.722*** (-4.44) -.584** (-3.59) -.583** (-3.58) Non-TFA teacher, nonstandard certified -.751 (-1.40) -.595 (-1.12) -.587 (-1.11) Total teaching experience .005 (.667) -.000 (-.054) -.000 (-.040) Masters degree or higher -.004 (-.031) .063 (.447) .065 (.461) Certification Date unknown .212 (.377) .177 (.319) .165 (.297) Classroom number of students .030 (1.41) .014 (.658) .013 (.643) Class average .626*** .627***


Education Policy Analysis Archives Vol. 13 No. 42 48 Variables Model A Model B Mode l C Model D Model E Model F previous year test score (47.47) (47.61) School-level variablesc % African American students in school -.082*** (-8.61) % Hispanic students in school -.089*** (-8.77) % free/reduced price lunch students in school -.006 (-1.15) Variance Components Level 1 (student) 106.32 72.71 72.12 72.12 72.13 72.13 Level 2 (classroom) 27.91 14.65 14.30 14.14 13.94 14.00 Level 3 (school) 19.77 10.01 8.81 8.84 20.88 17.37 Coefficients (and Robust T) and Variance Compon ents from Final Models (Modeled adjusted mean achievement only; all slope coefficients set as fixed) ~p<.10, p<.05, ** p<.01, ***p<.001 Reference Group for TFA/certification variables is Non-TFA teacher, standard certified Reference Group for student ethnic ity variables is White students a All student-level variables grand-mean centered, excep t, in Models E and F only, the previous year test score, which was group-mean centered in these two models. b All classroom/teacher-level va riables group-mean centered. c All school-level variables grand-mean centered.


Does Teacher Preparation Matter? 49 EDUCATION POLICY ANALYSIS ARCHIVES Editor: Sherman Dorn, University of South Florida Production Assistant: Chris Murre ll, Arizona State University General questions about ap propriateness of topics or particular articles may be addressed to the Editor, Sherman Dorn, Editorial Board Michael W. Apple University of Wisconsin David C. Berliner Arizona State University Greg Camilli Rutgers University Casey Cobb University of Connecticut Linda Darling-Hammond Stanford University Mark E. Fetler California Commission on Teacher Credentialing Gustavo E. Fischman Arizona State Univeristy Richard Garlikov Birmingham, Alabama Gene V Glass Arizona State University Thomas F. Green Syracuse University Aimee Howley Ohio University Craig B. Howley Appalachia Educational Laboratory William Hunter University of Ontario Institute of Technology Patricia Fey Jarvis Seattle, Washington Daniel Kalls Ume University Benjamin Levin University of Manitoba Thomas Mauhs-Pugh Green Mountain College Les McLean University of Toronto Heinrich Mintrop University of California, Berkeley Michele Moses Arizona State University Anthony G. Rud Jr. Purdue University Michael Scriven Western Michigan University Terrence G. Wiley Arizona State University John Willinsky University of British Columbia


Education Policy Analysis Archives Vol. 13 No. 42 50 EDUCATION POLICY ANALYSIS ARCHIVES English-language Graduate -Student Editorial Board Noga Admon New York University Jessica Allen University of Colorado Cheryl Aman University of British Columbia Anne Black University of Connecticut Marisa Burian-Fitzgerald Michigan State University Chad d'Entremont Teachers College Columbia University Carol Da Silva Harvard University Tara Donahue Michigan State University Camille Farrington University of Illinois Chicago Chris Frey Indiana University Amy Garrett Dikkers University of Minnesota Misty Ginicola Yale University Jake Gross Indiana University Hee Kyung Hong Loyola University Chicago Jennifer Lloyd University of British Columbia Heather Lord Yale University Shereeza Mohammed Florida Atlantic University Ben Superfine University of Michigan John Weathers University of Pennsylvania Kyo Yamashiro University of California Los Angeles


Does Teacher Preparation Matter? 51 Archivos Analticos de Polticas Educativas Associate Editors Gustavo E. Fischman & Pablo Gentili Arizona State University & Universidade do Estado do Rio de Janeiro Founding Associate Editor for Spanish Language (1998—2003) Roberto Rodrguez Gmez Editorial Board Hugo Aboites Universidad Autnoma Metropolitana-Xochimilco Adrin Acosta Universidad de Guadalajara Mxico Claudio Almonacid Avila Universidad Metropolitana de Ciencias de la Educacin, Chile Dalila Andrade de Oliveira Universidade Federal de Minas Gerais, Belo Horizonte, Brasil Alejandra Birgin Ministerio de Educacin, Argentina Teresa Bracho Centro de Investigacin y Docencia Econmica-CIDE Alejandro Canales Universidad Nacional Autnoma de Mxico Ursula Casanova Arizona State University, Tempe, Arizona Sigfredo Chiroque Instituto de Pedagoga Popular, Per Erwin Epstein Loyola University, Chicago, Illinois Mariano Fernndez Enguita Universidad de Salamanca. Espaa Gaudncio Frigotto Universidade Estadual do Rio de Janeiro, Brasil Rollin Kent Universidad Autnoma de Puebla. Puebla, Mxico Walter Kohan Universidade Estadual do Rio de Janeiro, Brasil Roberto Leher Universidade Estadual do Rio de Janeiro, Brasil Daniel C. Levy University at Albany, SUNY, Albany, New York Nilma Limo Gomes Universidade Federal de Minas Gerais, Belo Horizonte Pia Lindquist Wong California State University, Sacramento, California Mara Loreto Egaa Programa Interdisciplinario de Investigacin en Educacin Mariano Narodowski Universidad To rcuato Di Tella, Argentina Iolanda de Oliveira Universidade Federal Fluminense, Brasil Grover Pango Foro Latinoamericano de Polticas Educativas, Per Vanilda Paiva Universidade Estadual Do Rio De Janeiro, Brasil Miguel Pereira Catedratico Un iversidad de Granada, Espaa Angel Ignacio Prez Gmez Universidad de Mlaga Mnica Pini Universidad Nacional de San Martin, Argentina Romualdo Portella do Oliveira Universidade de So Paulo Diana Rhoten Social Science Research Council, New York, New York Jos Gimeno Sacristn Universidad de Valencia, Espaa Daniel Schugurensky Ontario Institute for Studies in Education, Canada Susan Street Centro de Investigaciones y Estudios Superiores en Antropologia Social Occidente, Guadalajara, Mxico Nelly P. Stromquist University of Southern California, Los Angeles, California Daniel Suarez Laboratorio de Politicas Publicas-Universidad de Buenos Aires, Argentina Antonio Teodoro Universidade Lusfona Lisboa, Carlos A. Torres UCLA Jurjo Torres Santom Universidad de la Corua, Espaa


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