USF Libraries
USF Digital Collections

Educational policy analysis archives

MISSING IMAGE

Material Information

Title:
Educational policy analysis archives
Physical Description:
Serial
Language:
English
Creator:
Arizona State University
University of South Florida
Publisher:
Arizona State University
University of South Florida.
Place of Publication:
Tempe, Ariz
Tampa, Fla
Publication Date:

Subjects

Subjects / Keywords:
Education -- Research -- Periodicals   ( lcsh )
Genre:
non-fiction   ( marcgt )
serial   ( sobekcm )

Record Information

Source Institution:
University of South Florida Library
Holding Location:
University of South Florida
Rights Management:
All applicable rights reserved by the source institution and holding location.
Resource Identifier:
usfldc doi - E11-00218
usfldc handle - e11.218
System ID:
SFS0024511:00218


This item is only available as the following downloads:


Full Text

PAGE 1

1 of 34 Education Policy Analysis Archives Volume 9 Number 21June 10, 2001ISSN 1068-2341 A peer-reviewed scholarly journal Editor: Gene V Glass, College of Education Arizona State University Copyright 2001, the EDUCATION POLICY ANALYSIS ARCHIVES. Permission is hereby granted to copy any article if EPAA is credited and copies are not sold. Articles appearing in EPAA are abstracted in the Current Index to Journals in Education by the ERIC Clearinghouse on Assessment and Evaluation and are permanently archived in Resources in Education .Impact of Grants-in-aid on Collegiate Education: Evidence and Implications of a Regional Study in In dia M. R. Narayana Institute for Social & Economic Change Bangalore, IndiaAbstract This article estimates the impact of grants-in-aid (GIA) and other variables on students' performance (in terms of pas s percentages) in aided private degree colleges, using panel data fro m sample colleges in Bangalore district of Karnataka State (India) from 1991-92 to 1997-98. In addition, sensitivity of a reduction in GIA on t he estimated pass percent of students in the individual colleges and feasibility of financing a reduction in GIA through proposed changes in stud ents' fee are analysed. The results show that (a) the impact of G IA is positive and significant in all estimations; (b) the estimated p ass percentage of students does vary remarkably, especially if GIA is reduced by 50 percent or more; and (c) the proposed fee revisions can finance a reduction in GIA to all colleges by about 12 percen t. The framework of analysis and implications of empirical results abov e are of relevance for other regions in India as well as for other develop ing countries in

PAGE 2

2 of 34assessing the policy impact of a reduction in publi c financing of higher education. 1. IntroductionCollegiate education in Karnataka State (India) com prises degree colleges which offer courses leading to the award of the Bachelor's degr ee in Arts/Science/Commerce/Education/Law by the Universi ty with which they are affiliated. The degree colleges include Government colleges and private aided and unaided colleges. An aided (or unaided) college is defined as that college which receives (or does not receive) grants-in-aid (GIA) from the State gov ernment. At present, the GIA is given only as a teaching/maintenance grant in the form of cent per cent reimbursement of salary for teaching and nonteaching staff. (Note 1) The main objective of this article is to examine wh ether or not the current GIA policy has influence on educational performance of aided c olleges, if that educational performance can be proxied by pass percentage of st udents in aided courses ? If so, what are the compulsions for the State Government to red ucing the GIA? Whether or not a size reduction in the current GIA to colleges in th e State is feasible? If feasible, how to implement such a policy of reduced GIA, without aff ecting the quality of education, through students' fee revision? (Note 2) In this article, a simple and general policy framew ork for empirical analysis of the nature and magnitude of determinants of performance of col legiate education, with special focus on the GIA, is developed. Second, the empiric ally framework is implemented for data on sample colleges in Bangalore Urban district (in brief, Bangalore district). Third, alternative policy scenario are generated by the te chnique of econometric policy simulation as to how a reduction in the GIA can inf luence the changes in the performance of collegiate education in the sample c olleges. In addition, the implications of financing a reduction in GIA through a revision in students' fee are analysed. The Bangalore district is one of the developed dist ricts in the State. (Note 3) Following the methodology of the UNDP in its human developmen t reports, the Government of Karnataka (1999: p.218) has recently constructed th e HDI by districts. For the year 1991, the value of HDI for Bangalore Urban district (or f or the State as a whole) is 0.601 (or 0.470) with the value of life expectancy index of 0 .680 (or 0.618), education index of 0.773 (or 0.596) and income index of 0.352 (or 0.19 6). Of the 20 districts, the rank of Bangalore Urban district is 2 in the value of HDI a nd in real GDP per capita (PPP$). This implies that the level of development of the d istrict is above the State level and most of the districts in the State. And, this good performance of the district is largely contributed by education index. Thus, a study and r ole of educational sector is of special importance for the development of Bangalore distric t in the State. And, collegiate education is and cannot be an exception for it.The main result of this article shows that the GIA policy has a positive and significant impact on educational performance of students in ai ded colleges. And, this result is valid for all estimated models of panel data. Surprisingl y, college-specific effects are found to be positive and statistically significant for indiv idual colleges, but not jointly significant for all colleges. Further, a cut in the size of GIA is shown to have differential impact on

PAGE 3

3 of 34students' performance in different colleges. Hence, a uniform cut in GIA for all colleges may not be a plausible policy in the State. Finally a proposed revision in the students' fee by the State government is shown to finance a r eduction in GIA of only about 12 per cent. Thus, students' fee cannot be a single instru ment for financing of entire reduction in the GIA.The results above are obtained from a particular sa mple of colleges within a region in India. However, the framework of analysis and natur e of problem are of general applicability for evaluation of regional education policy in other countries, especially if such countries are constrained to reducing public f inancing of their higher education, at present or in future. (Note 4)The rest of the article is organised as follows. Se ction 2 gives a brief review of literature. Section 3 outlines a framework for empirical analys is. In section 4, data and variables for estimation are detailed. Section 5 presents the estimation results. In section 6, the results of econometric policy simulation analysis a re discussed and major implications of financing a reduction in the GIA by revisions in students' fee are derived. Section 7 concludes the article with implications. 2. Review of literatureThere exists a vast literature on the determinants or correlates of student achievement (or performance or attainment) in schools, if not in co lleges, in India and in other countries. This literature provides a very useful information on various determinants and the nature and magnitude of effects of those determinants on s tudent performance in schools. These information are helpful as general guidelines for c urrent and future studies on determinants of student performance in schools in p articular and in colleges in general. In the context of India, Padma (1991) provides a ne at and comprehensive review of studies between 1983-88 on correlates of achievemen t. Broadly, the review divides the studies into variable-wise, educational level-wise and subject-wise. For instance, the variable-wise review of studies show both multiplic ity and diversity of variables used, such as, inherent variables (e.g. intelligence, per sonality, anxiety, feeling of insecurity, self-concept, motivation, academic interest, aptitu de, habits and attitude), sociological variables (e.g. socio-economic status and environme nt) and other variables (e.g. age at admission, language ability, medium of instruction, homework and dropout). On reviewing studies under subjectwise, Padma observ es that: "Each of the subjects is unique by itself. It is common experience to find a student achieving high in one subject of study while not doing so in some other. It is th erefore necessary to study achievement in different scholastic subjects" (p.813). Most recently, Duraisamy and Subramanian (1999) hav e estimated the determinants of higher secondary school attainment by courses and b y management of schools, using the sample survey data from Chennai metropolitan area. Using the framework of attainment production function, the authors estimate, among ot hers, the effects of child's sex and birth order, father's education, mother's education and family income, caste of the child, teacher's experience and sex, student-teacher ratio and management of school (i.e. whether private aided or unaided or public) on stud ent attainment in English and Mathematics separately. The estimation results, for instance, in regard to attainment in English showed statistically significant effects of all variables except sex of student and

PAGE 4

4 of 34teacher, student-teacher ratio. In particular, the positive and significant results in regard to management dummy-variable implied that "achievem ent scores of students from the private aided and unaided schools are much higher t han those from the public schools" (p.45). In addition, the authors make sample separa tion between public, private aided and private unaided schools, and estimate the effec ts of the same set of determinants above for the respective courses. The results show remarkable differences in the nature and magnitude of determinants between schools by ma nagement. Outside India, educational attainments are proxied by variables, such as, graduation rates (e.g. percent population graduated from high school ) and scores in standard achievement tests (e.g. Scholastic Aptitude Test). The broad gr oup of determinants is as follows. First, the school inputs or resources (e.g. pupil-t eacher ratio, level of teachers education, length of teachers education, expenditure per pupil class size, administrative inputs and facilities at schools). Second, family and/or paren tal background of students (e.g. parents income and educational level). Third, political and policy factors of the national and sub-national levels of governments (e.g. criteria f or financing public schools). Recently, Hanushek (1996) and Card and Krueger (199 6) provided an excellent review of micro and macro studies on the effects of the sc hool resources and family background on student performance in school in the context of USA. For instance, Hanushek's review summarizes, among others, the effects of tea cher-pupil ratio and expenditure per pupil on student performance from 277 and 163 studi es respectively. Surprisingly, of the studies using teacher-pupil ratio, only 15% (13%) o f studies report statistically significant positive (negative) effects, whereas 27 % (25%) of studies report statistically insignificant positive (negative) effects and 20% o f studies do not report signs of the statistically insignificant coefficient. In the sam e way, of the studies using expenditure per pupil, only 27% (7%) of studies report statisti cally significant positive (negative) effects, whereas 34% (19%) of studies report statis tically insignificant positive (negative) effects and 13% of studies report effect s with unknown signs. An important conclusion of Hanushek's extensive review is that s pending and commonly used resources of schools are not good measures of schoo l quality and, hence, merely adding such resources may not bring significant improvemen t in student performance. Thus, "the challenge is to identify the characteristics t hat make certain schools and teachers better, remembering that these characteristics don' t seem to have much to do with standard inputs, and then figure out how worse scho ols can take on these positive characteristics" (p.18). Further, Hanushek's review makes a useful analysis of the specification bias in using teacher-pupil ratio and expenditure per pupil when data on them are used at spatially aggregated levels. For instance, of the 277 studies in which teacher-pupil ratio is used, 157 studies were single State samples with 12% of t hem reporting statistically significant and positive (negative) sign. The remai ning 120 studies constituted multiple state samples with 109 studies which incorporate va riation within each State. And, 14% of these studies report statistically significant a nd positive effect of teacherpupil ratio. In the same way, the positive and statistically sig nificant estimates of expenditure per pupil is shown to be disproportionately contributed by studies employing data from inter-state samples and data aggregated at state le vel. Of late, Hammond (2000) has come out with a detaile d review and a strong evidence for the role of school variables (i.e. teacher quality) in determining student achievement.

PAGE 5

5 of 34The review of studies on teacher quality includes m easures of academic ability, years of education, years of teaching experience, subject ma tter and teaching knowledge, certification status, and teaching behaviour in cla ssroom. Using a large sample survey data at the state level in USA, a multiple-regressi on model is formulated to estimate the effects of teacher quality and other variables on s tudent achievement scores in mathematics and reading separately. The results sho w, among others, that the percent of well-qualified teachers has a positive and highly s ignificant effects on the achievement scores in all the subjects and grades included in t he estimations. From the literature review above, the evidence for the role and importance of policy and non-policy factors in influencing student performan ce in schools is clearly mixed. Further, the evidence is relevant for particular so cio-economic context, educational level, institutional setting and data availability in the respective countries. These evidence have two implications. First, empirical an alysis on the determinants of student performance needs to be continued, as the available evidence (either supporting or confronting) are not conclusive. Second, unless the socio-economic context, educational level and institutional setting are comparable, a r eplication of previous studies may not be relevant for a current or future study. Third, t here exists no econometric study on the impact of GIA on collegiate education in Karnataka State, or in other states of India, especially as they are related to the issues in the GIA policy above. (Note 5) In the same way, no published study on this topic of educationa l finance seems to be available outside India. Thus, an empirical analysis of effec ts of college resources on student performance in Karnataka needs a new framework, as no previous study exists on this topic to fill in these research gaps. 3. A framework for empirical analysisWe consider that the ultimate and sole objective of a college is to turn out the students with a successful graduation. Since passing the fin al examination, given that all other/previous examinations had been successfully p assed, is a precondition for graduation, it is plausible to consider that the nu mber of students passing the final year examination as a proxy for the number of graduates. From this viewpoint, a college should aim at achieving a 100 percent graduation of its students. Note that within the graduated students, there exists heterogeneity in t erms of passing the degree examination with a I Class or II Class or III Class. Since clas s distinctions are not essential to obtain a degree, they are ignored throughout.Let P it be the total number of students who have passed the final year examination as a percentage of total number of students who appeared for that examination in the i-th college for the t-th year. Throughout, this percent age will be referred to as the pass percentage and would be the sole indicator of educa tional performance of a college. We consider that P it is a function of GIA and nonGIA variables. And, d enote the non-GIA variables as (X 1it ,….,X mit ) and the GIA variable as GIA it If data on P it (X 1it ,….,X mit ) and GIA it are available for N-number of colleges and Tnumb er of years, the following panel data model may be formul ated.

PAGE 6

6 of 34 ……….(1)where the total number of observations equals to NT (Note 6) The panel data thus generated in (1) can be employe d for estimation of alternative models, such as, a pooled regression model and fixe d effects model. Assuming P it is linear in both variables and parameters, a pooled r egression model can be formulated as follows. …..(2)where both the intercept ( b 0 ) and slope ( b j 's) coefficients are presumed to be constant, both across colleges and over time; and m it is the random disturbance term. It is assumed that the model in (2) satisfies all the standard as sumptions of a multiple (linear, ordinary and normal) regression model. Hence, (2) is estimab le by the technique of ordinary least squares. In a fixed effects model (FEM), the coefficients (i .e. intercept coefficients) are considered to be non-random or fixed but unknown. A nd, the unknown parameters are to be estimated. A simple framework for estimation and testing of a FEM is as follows. ……….(3)This model allows for the intercept to vary across colleges but not over time. And, the slope coefficients are assumed constant, both acros s colleges and over time. (Note 7) In essence, the fixed effects in (3) are presumed t o account for those omitted variables that are specific to individual-colleges. One possi ble explanation for the omission of such variables is lack of information on them for a rese archer, such that they become totally unobserved. These unobserved variables might includ e dedicated teaching and non-teaching staff, commitment for learning on the part of the students, opportunities for professional interaction and growth, and existenc e of benevolent college management.

PAGE 7

7 of 34In estimating the model in (3), we follow the least square dummy-variable approach, where separate dummyvariables are introduced for each of the N-colleges. Thus, the total number of coefficients to be estimated in equ ation (3) is N-dummy coefficients + number of slope parameters. In the ultimate analysis, the formulation above inv olves a choice between the pooled regression and fixed effects model. For this purpos e, we adopt the following test in Green (1997). Let the estimated coefficient of determinat ion or R 2 in (3) be denoted by R 2 (FEM) and R 2 (PRM) be the estimated R 2 in (2). Let M* be the number of explanatory variables excluding the intercept. Then, null hypot hesis of whether the fixed effects are the same for all colleges can be tested by the foll owing F-test …..(4)4. Data and variables for estimation 4.1. Data for estimationCollegiate education in Karnataka includes general degree colleges, law colleges and education colleges. (Note 8) This study, however, i s focused only on general degree colleges which are aided. The panel data on the colleges for 7 years, from 19 9192 to 1997-98, were collected by developing and canvassing a structured questionnair e to aided colleges in Bangalore district. (Note 9) According to Government of Karna taka (1998), there were 44 aided degree colleges in the Bangalore Urban district and 4 in Bangalore Rural district during 1997-98. In total, 35 colleges were randomly select ed. Over a period of four months and by the end of December 15, 1998, the completed ques tionnaires were received from 30 colleges in Bangalore Urban district and 1 college in Bangalore rural district. Thus, the sample colleges essentially belong to Bangalore Urb an district only. In addition, the sample comprises colleges of all types of private m anagement in the district, viz., 2 SC/ST colleges, 9 Minority colleges and 20 other co lleges (i.e. neither SC/ST nor Minority colleges). 4.2. Variables for estimation To start with, from the sample survey of colleges a bove, the following variables are listed for consideration of estimations. Throughout, unles s stated otherwise, by courses we mean only the aided courses and by colleges we mean only the aided colleges. 4.2.1. Dependent variable

PAGE 8

8 of 34The dependent variable in all estimations is the pa ss percentage of students in all courses (PASS%) in a college. This is defined as the total number of students in the courses who have passed the final year examination in B.A. B.Sc and B.Com as a percentage of total students in the final year of the B.A. B.Sc and B.C om. In principle, pass percent of students in a college may be defined in two alternative ways. The notations to be used in these definitions are a s follows. Let P jit be the total number of students passing the final year examination of t he j-th course in the i-th college and in the t-th year. And, S jit be the total number of students in the final year of the jth course in the i-th college and in the t-th year, and T it is the sum of students in all courses [i.e. T it = S j (S jit )]. Throughout, j=1,2,3; i=1,2,….,31; and t=1,2,….,7.First, the pass percent of student by courses (PASS %) jit ……(5)Second, the pass percent of student for all courses in a college (PASS%) it ……(6)In general, (PASS%) jit (PASS%) it unless j=1. Further, ……(7)Hence, (PASS%) it is the weighted sum of (PASS%) jit where the weight is the ratio of final year students in a course to total number of final year students in all courses in a college. In my estimations, the dependent variable is (PASS% ) it in (6) rather than (PASS%) jit in (7). This is due to the following institutional fac tors and data problems. 4.2.1.1.Institutional factorsIn Karnataka State, colleges impart education leadi ng to the award of Bachelor's degree in Arts, Science and Commerce (B.A. B.Sc and B.Com res pectively) by the University with which they are affiliated. For instance, colleges i n Bangalore districts are affiliated with Bangalore University. The major functions of the Un iversities include the preparation of common syllabus, conduct common examination and eva luation and award degrees for successful students in different courses.

PAGE 9

9 of 34Each of the degree courses contains different subje cts. For instance, B.A. course contains all subjects under humanities and social sciences, such as, languages, history, economics, political science, philosophy and sociology. Each of the subjects contains different papers. The number of papers in different subjects may be uniform within a course. The minimum marks t o pass in a subject may be set by the University to a common level (e.g. 35%). Thus, to pass in a subject the minimum marks to be obtained is 35% in all subjects, and to graduate (or, to obtain a degree), the minimum marks to be obtained is 35% in all subjects In short, the minimum marks for graduation is uniform for all courses within a coll ege and in the University. Consequently, my article has presumed that efforts to pass is uniform across papers, subjects and courses. Accordingly, pass percent of students for all courses (or graduation rate) in a college is considered to be a plausible specification of the dependent variable in my estimations. Here I might add the fact that, as compared to coll egiate education, school education is simpler in structure and uniform throughout the Sta te. For instance, high school education in the State is a three year course, star ting from the 8 th standard and ending with 10 th standard. In the 10 th standard, State level public examination is held w ith all students preparing for the same number of papers wi th common syllabus, and common examination and evaluation held at the same time th roughout the State. There is no difference between a paper and subject in high scho ol education, as each subject has only one paper. Thus, studies on determinants of student performance in Indian schools have used data by courses rather than for all courses to gether [e.g., Duraisamy and Subramanian (1999)].4.2.1.2.Data problemsFirst, of the 31 sample colleges, only 9 colleges h ave all the three degree courses. In the remaining 22 colleges, B.A. course is given in 19 c olleges, B.Com in 22 colleges and B.Sc in 9 colleges. Further, in many colleges, diff erent courses are observed to have been started in different years. Thus, course-wise infor mation on student performance is not constructable for all 7 years and for all colleges. Second, the sample survey did not attempt to collec t information on student performance by courses. Hence, course-specific determinants are not possible to be estimated from the information in my sample survey of colleges. 4.2.2. Independent variablesThe independent variables include the GIA and non-G IA (in the form of qualitative and quantitative) variables. (i) Year of starting a college (START): Colleges in Bangalore district have been started in different years and some of them have been in exist ence over 25. Such old colleges may have developed better infrastructure as compared to colleges which have been started more recently. To capture the impact of different y ears of starting of colleges on PASS%, START is introduced as a dummyvariable [=1 (or 0) if the college is started in or

PAGE 10

10 of 34before 1970 (or if started after 1970]. (ii) Composition of students in a college (COM): Co lleges are different in regard to the composition of students. For instance, there are wo men's colleges, men's colleges and co-education colleges. There is a presumption that, other things being equal, pass percentage of students is higher in women's college s than in other colleges. To test the validity of this presumption, COM is introduced as a dummy-variable [=1 (or 0), if the college is a women's (or men's/co-education ) colle ge]. (iii) Courses offered (COURSE1): The nature and num ber of aided courses (apart from unaided courses, if any) differ between colleges. F or instance, a college may offer only B.A. and B.Com courses, and another college may off er B.A. B.Com and B.Sc courses. Since the dependent variable is the pass percentage of students in all aided courses, it makes a difference whether or not a college has all the three aided courses. To capture the same, COURSE1 is introduced as a dummy variable. It s value is equal to 1 (or 0) if a college offers B.A., B.Sc. and B.Com courses (or if it offers only one or two of the three degree courses]. (iv) Course offered (COURSE2): The presence of B.Sc course is often presumed to be a major contributory factor for the overall pass perc entage of students in a college. To test this presumption, COURSE2 is introduced as a dummy variable. Its value equals to 1 (or 0) if a college offers B.Sc. and/or B.A., and/or B. Com courses (or if offers B.A. and/or B.Com course. (v) Year of GIA (YGIA): As in the case of the year of starting of colleges, there is a considerable variation in the year of bringing the colleges under the GIA. If a college had been brought under the GIA before 1977, it might ha ve been better endowed with teaching and nonteaching staff and facilities tha n colleges, which have been brought under the GIA since 1977. This is because of the fa ct that before 1977, the GIA was also given for assisting the non-staff requirements (e.g purchase of site, construction of buildings and purchase of equipment) of the college s. To capture the effects of difference in the year of receiving the GIA, YGIA is introduce d as a dummy variable [=1 (or 0), if the year of bringing the college under GIA is in or before 1977 (or after 1977]. (vi) Ratio of final year students to first year stu dents (RSFFY): This variable is defined as the number of students in the final year B.A. B.Sc and B.Com as a ratio of total number of students in the first year B.A. B.Sc. and B.Com course in a college. This variable is intended to capture the nature and magnitude of the impact of retention of students on the PASS% in the colleges. (vii) Student-teacher ratio (STR): This is the rati o of total number of students studying in I, II and III year of B.A. B.Sc and B.Com course to the total permanent teaching staff who are involved in these courses. In short, STR is the total number of degree students per permanent teacher in the aided courses of a college The STR is intended to capture the availability of per teacher services for students, which is a vital input for students' performance, in the colleges. (Note 10) (viii) Amount of standardized GIA (SGIA): This is t he amount of nominal GIA in the standardized form. That is, the actual observations on the nominal GIA are subtracted from its arithmetic mean and the resultant value is divided by the standard deviation of the GIA. The basic purpose of the standardisation i s to convert the GIA into a

PAGE 11

11 of 34dimensionless quantity such that it does not vary a long with its unit of measurement. This type of standardization is especially relevant since the observed values of the total GIA to individual college vary considerable in cros s-section and time series data. These variations are accountable for many factors (e.g. n umber of aided courses and teachers, years of experiences of the teachers, allowances re lated to inflation and number of any part-time or temporary staff). Thus, using the abso lute amount of the GIA may not be plausible. Further, any attempt to express the GIA in different units of measurement (e.g., in thousand or lakh of rupees) would result only in different magnitude for the estimated coefficient for the variable. Thus, it is necessary to standardize the variable such that its value does not vary with the unit of measurement. (ix) Amount of standardized non-salary and wage exp enditure (SNTE): This is the amount of nominal expenditure on non-salary and wag es in a college and the nature of standardization is the same as explained in (viii) above. In addition, non-salary and wage expenditure per student (NTEPC) is considered as an alternative variable for SNTE. It is important to note that not all the quantitati ve and qualitative variables above are included in the final estimations. For instance, th e variables which are dropped from the final estimations, and the main reason for the same are given below. First, there exists a perfect colinearity between START and YGIA. Thus, e stimations including both the dummy-variables in the same equation is not possibl e. Second, inclusion (either separately or in combination) of PCNTE and SNTE did not improve the qualitative aspects of the trial estimation results and, hence, dropped from further estimations. Consequently, the following independent variables a re chosen for final estimations: COM, COURSE1 or COURSE2, YGIA, RSFFY, STR and SGIA. At the very outset, the inclusion of both STR and S GIA in the same equation may mean the double counting of the effects of GIA on the PA SS%. This is due to the fact that a part of total permanent teachers in the aided colle ges/courses are paid salary from the GIA. However, in our estimations, this problem of d ouble counting is avoided by aiming to capture separate effects of STR and SGIA on the PASS% as explained below. First, given the number of students, STR merely dep ends and varies between colleges on the number of teachers. Hence, it does not distingu ish the quality of teachers in terms of their higher qualification and longer experience. T hus, if two colleges have equal number of total students and teachers, except that in one college there is a large number of experienced teachers, the STR will be equal between colleges although the quality of teaching may differ between colleges. Second, the SGIA is intended to capture the incenti ves for and quality of teachers in a college as contributed by the GIA policy. For insta nce, apart from the basic salary, it captures the incentives (e.g. pay revisions) and co mpensations (e.g. inflation-linked DA payments) for the teaching staff. Thus, if two coll eges have the same number of teaching staff but different amount of GIA, then a college, which has a larger GIA, may comprise more number of experienced staff. These effects of the GIA policy, however, would remain uncaptured if GIA were not included as a sep arate explanatory variable. 4.3. Predictions

PAGE 12

12 of 34First, we predict the sign for the coefficient for RSFFY to be negative. This result may be interpreted that, other things being equal, a decre ase in the number of students in the final year as a percentage of students in the first year would have a negative effect on the pass percent of students in the final year examination. This is plausible since a decrease in RSFFY may be contributed by a higher number of good performing science students, who might have left the degree course to joining pr ofessional courses. Second, we predict the sign of the coefficient for STR to be positive. This result may be interpreted that, other things being equal, an incr ease in the number of teachers would have a positive impact on pass percent of students in a college. This is plausible since, for a given number of students, an increase in the numb er of teachers means a greater amount of teaching time for and interaction with the stude nts. Third, we predict the sign of the coefficient for S GIA to be positive. This result may be interpreted that, other things being equal, an incr ease in one standard deviation of the GIA would have a positive impact on the pass percen tage of students in aided courses. Such a result would clearly demonstrate that the pr esent GIA policy is positively contributory for the educational performance in the colleges. In regard to three dummy variables [COM, COURSE1 or COURSE2 and YGIA], the interpretation of estimated results depends on thei r assigned values (i.e. 1 or 0). Accordingly, the expected or mean value of the PASS % may be interpreted, either individually or for a combination of these dummy va riables. For instance, the estimated coefficient for COURSE1 shows the extent by which t he mean PASS% in a colleges, which offers all the degree courses, differs from t he mean PASS% in college which offers one or two of the degree courses. Further, if COM=1 ; YGIA=1; and COURSE1=1, and other things being equal, we obtain the mean PASS% in a college, if that college were be a women's colleges, offering all the degree courses and brought under the GIA before 1977. 5. Results of estimation5.1. Descriptive statistics The descriptive statistics for the quantitative var iables (i.e. PASS%, RSFFY, STR and SGIA) are given in Table 1. By definition, the mean and standard deviation of the SGIA is 0 and 1 respectively. Hence, coefficient of vari ation cannot be computed. Table 1 Descriptive Statistics

PAGE 13

13 of 34 First, the largest variation (in relative terms) is evident for STR and the least variation is evident for RSFFY. Second, the range of STR is wide as the maximum (or minimum) value is about 165 (or 7). Most importantly, the ra nge of values of SGIA is smallest among all the variables. This is the outcome of the standardization applied for the absolute GIA for sample colleges. Note that the min imum value for the SGIA is negative. This is possible if grants-in-aid to a college are less than the average value of grants-in-aid for all colleges. Next, the simple correlation coefficients show the nature and degree of linear relationships between variables. For instance, the PASS% is positively (or negatively) correlated with STR and SGIA (or RSFFY). In fact, t he correlation coefficient between PASS% and SGIA is the highest among all the positiv e coefficients. And, SGIA is negatively correlated with STR and RSFFY.5.2. Estimation results of the pooled regression mo del Table 2 summarizes the estimation results of pooled regression model. The estimation results with COURSE1 show that the e stimated coefficients of RSFFY, STR and SGIA have predicted signs and are statistic ally significant at 5 percent level. In addition, the estimated coefficient of the dummy va riable, COM, is positive and highly significant. Thus, the mean pass percentage of stud ents in women's college differs from the mean pass percentage of students in a men's or co-education college by 15.73 percent. Further, the explanatory power in terms of R 2 is about 32 percent. This indicates that about 32 percent of variations in the PASS% are exp lained by the included variables in the model. This is supported by the highly signific ant F-statistic in the estimation. Table 2 Estimation Results of the Pooled Regression Model

PAGE 14

14 of 34 Interestingly, the estimation results above are qua litatively and quantitatively different when COURSE1 is replaced by COURSE2 as an explanato ry variable. Thus, the presence or absence of B.Sc course does make a diff erence in the mean PASS% of students. Nevertheless, the estimated coefficient f or COURSE 1 or COURSE2 is not statistically significant in both the estimations. Further, in both the estimated equations, the coeff icient of the YGIA remains insignificant. Thus, the year of the GIA in/before 1977 or after makes no difference for the pass percentage of students. Further, it is imp ortant to note that the estimated intercept term is positive and significant. To capt ure the variation in this coefficient between colleges is the focus of the following esti mation of FEM. 5.3. Estimation results of fixed effects model The results of the FEM in Table 3 show that the est imated coefficient for COM, RSFFY, STR and SGIA are significant. In addition, the esti mated fixed effects are positive and significant for each of the 31 colleges. The magnit ude of the estimated fixed effects is clearly different between colleges. This result off ers evidence for the importance of college-specific effects (unobserved, however) on t he pass percentage of students.Table 3 Estimation Results of the Fixed Effects Model

PAGE 15

15 of 34 As in the case of pooled regression, the estimated coefficient for RSFFY, STR and SGIA are significant and possess predicted sign. However the magnitude of the estimated coefficient for RSFFY and STR (or SGIA) are smaller (or larger) in case of FEM. In the same way, the sign and magnitude of the estimated c oefficient for COURSE2 is different between the pooled regression model and FEM. In par ticular, the estimated coefficients for COURSE and YGIA remain insignificant in both th e estimation models. In addition, the R 2 for the FEM is 0.40, which is higher than the R 2 for the pooled regression model (=0.32). Thus, the explanatory power of the FEM is higher than the pooled regression model.

PAGE 16

16 of 34Using the framework in equation (4) above, we test whether or not the fixed effects are the same for all the colleges. The computed value o f F-statistic is 0.79. Since the 5 percent critical value of F(30, 180) is about 1.46, we do not reject the null hypothesis that fixed effects are the same at the 5 percent level o f significance. Thus, on empirical grounds, college-specific effects are individually significant but not jointly for all the aided colleges. This implies that the estimators of pooled regression in Table 2 are efficient as compared to the estimators of FEM in T able 3. It should be emphasised that the impact of SGIA is positive and significant in the estimations above. This result offers empirical evi dence for the positive role of the GIA policy on the educational performance of aided coll eges in Bangalore district. Since the basic objective of the GIA policy is to improve the educational performance of colleges, the estimation results offer unambiguous evidence i n favour of accomplishing this objective of the GIA policy in aided colleges of Ba ngalore district. (Note 11) 6 Impact of a reduction in GIA A reduction in GIA may influence the PASS% in two i mportant ways. First, by affecting STR through a reduction in the number of permanent teaching staff or number of teacher hours for a given number of students. Second, by af fecting the quality of teaching through a reduction in incentives to work due to loss of re gular salary and benefits as well as job security. However, if the teaching staff on the GIA is all permanent staff, then a reduction in GIA may not automatically translate itself into a reduction in number of staff or reduction in teaching work. Rather, it may affect t hose staff who are temporary or part-time basis and are paid by the college managem ent. In this situation, a reduction in the GIA may not affect the STR as the denominator o f the STR comprises only the permanent staff. Thus, in what follows, we attempt to capture the impact of a reduction in GIA only in terms of changes in SGIA but not throug h changes in STR. The impact analysis below is framed as a simulation exercise to answering the following policy question. What would have been the pass perc entage of students from 1991-92 through 1997-98, if the values of the SGIA were to be less than what were observed in those years and given the value of other independen t variables as they were observed ? In particular, we determine the impact on the estimate d PASS% if the SGIA to the colleges were to be reduced by 10 percent or 25 percent or 5 0 percent or 100 percent. This analysis helps in identifying the impact of SGIA on PASS%, separately for individual colleges. (Note 12)The framework for the simulation analysis is as fol lows. First of all, we have the following estimated equation from the FEM, wherein the capped coefficients are the estimated coefficients from Table 3; and the capped P it the estimated mean PASS% of students in the i-th college for the t-th year. ……….(8)

PAGE 17

17 of 34Thus, for each of the 7 years, the estimated PASS% may be computed for each of the 31 colleges. It should be noted that the nature of changes in PA SS% due to a reduction in SGIA depends on whether the actual GIA is above or below the arithmetic mean of the GIA to the colleges. For those colleges where the actual G IA is less (or greater) than the arithmetic mean of the GIA for all colleges, the va lue of SGIA is invariably negative (or positive). Hence, the impact of an increase or decr ease in SGIA is negative (or positive) respectively. In view of this, the simulation resul ts should only be considered for understanding the sensitivity of changes only in th e absolute magnitude of PASS%. 6.1. Simulation resultsTable 4 presents the simulation results for the yea r 1991-92, 1994-95 and 1997-98. Given the estimated coefficients and observed values of i ndependent variables, the estimated PASS% is obtained. And, alternative values of estim ated PASS% are obtained depending on the extent of assumed changes in SGIA. The major results and implications of the analysis are as follows. Table 4 Impact of Changes in the GIA on PASS% During Select Years: Results of Econometric Policy Simulation Analysis

PAGE 18

18 of 34 Table 4 (Continued) Impact of Changes in the GIA on PASS% During Select Years: Results of Econometric Policy Simulation Analysis

PAGE 19

19 of 34 Table 4 (Continued) Impact of Changes in the GIA on PASS% During Select Years: Results of Econometric Policy Simulation Analysis

PAGE 20

20 of 34 First, the estimated PASS% differs between years an d between individual colleges. The maximum (or minimum) estimated PASS% is 71.13 (or 1 9.74) during 1991-92, 69.64 (or 17.06) during 1994-95 and 64.72 (or 19.44) duri ng 1997-9. However, the estimated PASS% does not differ in absolute deviations. For i nstance, the value of the standard deviation is about 12 for estimated PASS% for all t he select years. This implies that the absolute variation in the estimated PASS% remains t he same, whether or not there are any individual variations in the SGIA. Second, the reduction in SGIA does matter for the c hanges in the PASS% for individual colleges. This is reflected in the absolute differe nce between the estimated PASS% and estimated PASS% under alternative reduction in SGIA in all the years. In particular, in many colleges, the estimated PASS% does vary remark ably when the SGIA is reduced by 50 percent or more. These colleges include No.3, 4, 5, 17 and 27 during 1991-92; No.4,5,8,9 and 13 during 1994-95; and 4,5,8,13,14 a nd 22 during 1997-98. These

PAGE 21

21 of 34colleges, however, may not be subject to a reductio n in the GIA as the reduction may not be effected without compromising on the quality of education, or students' performance, in them.6.2. Financing the reduced GIA by students' fee rev ision The first report of Human Development in Karnataka 1999 [Government of Karnataka (1999)] has various agenda for future action in edu cation in Karnataka. For instance, the agenda for Colleges and Tertiary education includes : "Make colleges more self-financing by enhancing fees". In fact, the nee d for fee revision in colleges/higher education has been argued frequently in Karnataka. For instance, the State Planning Board's paper on An Approach to Subsidies in Karnat aka in 1997 has clearly noted: "It is estimated that hardly 1/5 th of the Government expenditure on higher/university education in the country is recovered by way of fee s etc. This means 80 per cent of the cost of the higher education is subsidized. It shou ld be possible to reduce the extent of subsidy in higher education without affecting the s ervices. It is therefore necessary to aim at revising upwards the fees and other payments for higher education in such a way that at least 75 to 80% of the cost of the services are recovered in the long run which can be attempted in phases” (pp.26-27). In the argument s above, there is an implicit assumption that self-financing is equivalent to ful l cost recovery through students' fee revisions, and such self-financing should ultimatel y aim at replacing State's budgetary support to higher education. However, the validity of this assumption is not tested with conclusive evidence. In what follows, we test this hypothesis by considering a case for financing of a reduction in GIA through students' f ee revisions, as proposed by the State government, in the colleges. (Note 13) The Government of Karnataka [Annexure to G.O.No.ED123-UEC-97, dated 21.06.1997] has proposed the following revisions to students' fee, as applicable from the academic year 1997-98, for both aided and unaided c olleges. These rates are called proposed rates below as they are yet to be implemen ted. Figures in the parentheses are the current rates, [revised in and implemented sinc e 1993-94]. (i) Application fee Rs.10 (Rs.5); (ii) Admission fee Rs.100 (Rs.10); (iii) Tu ition fee Rs.600 (Rs.180); (iv) Laboratory fee Rs.400(Rs.80); (v) Reading room fee Rs.100 (Rs.30); (vi) Sports fee Rs.100 (Rs.30); (vii) Library fee including binding changes Rs.100 (Rs.5); (viii) Mid-term examination fee Rs.100 (Rs.5); (ix) Studen ts Welfare Fund Rs.10 (Rs.5); (x) Teacher's Welfare Fund Rs.10 (Rs.5). In principle, the tuition and laboratory fee is permitted to be doubled. And, to lessen the burden of payment all fee at once, the total fee of Rs.1530 is to be paid in two installments. T he first installment (Rs.1030) is at the time of admission. The second installment (Rs.500) is in October/November of the year. In terms of the existing policy, tuition fee is tot ally exempted for SC/ST students. Further, there is no laboratory fee for students of B.A. and B.Com course. Hence, according to current rates (or proposed rates) the following total fee is applicable for students. First, according to current minimum rates Rs.95 (or Rs.275) for SC/ST (or other) students in B.A. or B.Com; Rs.175 (or Rs.355 ) for SC/ST (or other) students in B.Sc. Second, according to proposed minimum rates, Rs.530 (or Rs.1130) for SC/ST (or other) students in B.A. or B.Com; Rs.930 (or Rs.153 0) for SC/ST (or other) students in B.Sc.In Table 5, a simple calculation is presented for t he amount of fee income to the sample

PAGE 22

22 of 34colleges, if they were to implement the revised rat es at the minimum of tuition and laboratory fee during 1997-98. Column 2 through col umn 7 present the basic data on the number of SC/ST and other students, admitted to deg ree courses by individual colleges. These data are essential since the total fee collec tion depends on the number and nature of students by courses (especially non-SC/ST studen ts in B.Sc. course). Table 5 Financing of the Reduced GIA through Fee Revision: Some Alternative Policy Scenarios for 1997-98 Table 5 (Continued)

PAGE 23

23 of 34Financing of the Reduced GIA through Fee Revision: Some Alternative Policy Scenarios for 1997-98 Table 5 (Continued) Financing of the Reduced GIA through Fee Revision: Some Alternative Policy Scenarios for 1997-98

PAGE 24

24 of 34 The total collectable fee income from admission to I year of all aided courses are presented in column 9 and 10, when the tuition and laboratory fee are at the minimum. Note that in these computations, the SC/ST students are exempted from the tuition fee by the colleges. These exemptions account for foregone fee income fo r the colleges and not reimbursed by the Government. If reimbursed, the total fee income to the colleges would be higher than what have been reported in column 9 and 10. Next, the increase in total fee income for colleges in moving from the current rates to the

PAGE 25

25 of 34proposed rates is remarkable, as shown by the numbe rs in column 11. However, there exists a wide variation in the absolute amount of t otal fee collectable by the individual colleges for differences in the number of courses a nd students. Further, as a percentage of the GIA, total fee inco me under different rates shows considerable variations as reported in column 12 th rough column 15. The highest (or lowest) percentage is 12.84 (or 0.44) according to the current rates. For the proposed rates, three cases are considered. Case 1 is when the tuit ion and laboratory fee is at the minimum. Case 2 is when the tuition fee is doubled (or at the maximum). Case 3 is when both tuition and laboratory fee are doubled. In the analysis above, the proposed fee were to be applicable only for new admissions during 1997-98. But for students who are already in II year and III year aided courses, the existing fee is applicable. Thus, the total fee col lectable from the entire aided courses equals to the sum of (a) fee collectable according to the proposed rate from the I year students and (b) fee collectable according to the e xisting rates from II year and III year of the aided courses during 1997-98. If, for the sake of simplicity, the number and comp osition of students is the same in all the three years of the course, then the total fee colle ctable from all students in all aided courses are given in column 16 through column 21. These fig ures indicate the upper limit for collectable fee as they are calculated by charging fee for all students and by assuming zero dropouts from the courses. Thus, the proposed rates even if were to be totally implemented, cannot totally fill in the resource ga p, except in case of college no.12, if such a gap is created by complete withdrawal of current GIA to the colleges. Nevertheless, the figures in column 16 through colu mn 21 indicate the extent to which the current GIA to colleges can be withdrawn in varying amount under the proposed rates, but to leave the colleges resource-neutral or quality-n eutral. For instance, the sum of reduced GIA to all sample colleges equals to about Rs.80.41 lakh (1 lakh=100000) according the current rates; Rs.167.51 lakh under Case 1, Rs.181. 72 under Case 2 and Rs.182.84 lakh under Case 3 of the proposed rates. As a ratio to t otal GIA for all sample colleges (=Rs.1624 lakh), the reduced GIA accounts for 4.95 percent according to current rates; 10.31 percent under Case 1, 11.19 percent under Cas e 2 and 11.26 under Case 3 of the proposed rates. Thus, if the revised rates are impl emented under Case 2 or Case 3, about 12 percent of the current size of GIA can be reduce d to the sample colleges. It should be emphasized that total collectable fee and the amount of GIA vary between colleges. This, in turn, implies that the ability o f individual colleges to finance a reduction in GIA by fee revision also varies between colleges Hence, a uniform cut in GIA for all colleges may not be practicable. Second, at present only GIA net of tuition fee is distributed to colleges. However, the entire analys is above takes both tuition and non-tuition fee as instruments of financing a reduc tion in the GIA. Interestingly, according to the current (proposed) rates, the tuition fee ac counts for about 65 (50) percent of annual total fee for B.A. and B.Com courses, and 53 (39) p ercent of total fee for B.Sc course. From this viewpoint, the impact of fee revision on financing GIA will be far less than the figures in the Table 5. 7. Conclusions and implications

PAGE 26

26 of 34This article has developed alternative empirical fr ameworks for estimating the impact of GIA and non-GIA variables on the pass percent of st udents in all aided courses, viz., a pooled regression model and a fixed effects model. Further, a policy simulation framework is developed for assessing the impact and sensitivi ty of a reduction in GIA on the estimated pass percent of students in the individua l aided colleges. In addition, impact of financing the reduced GIA within the framework of e xisting and proposed policy changes in regard to the students' fee in degree colleges i s analysed. The frameworks thus developed are estimated for dat a from 31 sample aided colleges in Bangalore districts. The estimation results show th at, regardless of the nature of estimation in terms of pooled regression and FEM, the impact o f COM, RSFFY, STR and SGIA on the PASS% is significant. Second, the impact of SGI A is positive and significant in all estimations. Given that one of the objectives of th e GIA policy is to improve the educational performance of colleges (e.g. in terms of improving the pass percentage of its students), this result offers unambiguous evidence in favour of accomplishing this basic objective of the GIA policy in the State. Third, th e college-specific effects are positive and significant for individual colleges but not jointly for all aided colleges. The results of the econometric policy simulation an alysis show that the estimated PASS% differs between years and between individual colleg es in the State. And, these estimated PASS% do vary remarkably with variations in the SGI A, especially when the SGIA is reduced by 50 per cent or more. However, in many co lleges, the variations are considerable. Such colleges are underlined to be se nsitive to reduction in the GIA. Thus, a uniform cut in GIA for all colleges is not a realis tic approach to reducing the GIA. It is demonstrated that if the proposed fee revisio n is implementable, the GIA to a college can be cut proportionate to the increase in fee inc ome. In this case, a reduction in GIA shall not affect the quality of education in the ai ded colleges. However, the proposed fee revisions can finance a reduction in GIA to all col leges only to the extent of about 12 percent. Thus, students' fee cannot be a single ins trument for replacing GIA in the State. This suggests a need for exploring additional sourc es of financing the colleges, especially private funding for colleges. (Note 14) Other things being equal, and if the present GIA is continued, there exists a lesser compulsion for the aided colleges to implementing t he revised fee structure, provided the aided colleges have the complete freedom in impleme nting the revised fee. Rather, if the present GIA is to be gradually reduced, there may e xist a natural compulsion for the aided colleges to implementing the revised fee, at least to recover the losses arising out of reduced GIA. From this viewpoint, a reduction in GI A can be an instrument for implementing the revised fee above. The entire policy analysis in this article has been based on the supply side factors, given the demand for collegiate education including that all students are equally willing and capable of paying the proposed rates. In the absenc e of this assumption, effects on demand and distributional implications of implementing the proposed fee may have to be carefully worked out (especially, access to collegiate educat ion for the poor students), before any revision to the current rates is effected. (Note 15 ) In reality, many external effects may influence stu dents' performance in a college. First, when a class comprises both merited and less merite d students, there are external effects

PAGE 27

27 of 34on each other within a class. Second, the presence of unaided courses along with aided courses in aided colleges may generate external eff ects on each other within a college. Third, presence of several colleges in close proxim ity may generate external effects on students' performance between colleges within an ur ban area. Exploration of these external effects is an interesting extension of this article (Note 16) The framework of analysis and nature of problem in this article are of general applicability for other developing countries where the government s are constrained to reducing public financing of higher education. If studies in other countries are undertaken, alternative evidence (either supporting or confronting) can be established for the hypotheses tested here. NotesAn early version of this article was presented for South Asian Conference on Education, held at Delhi University [Delhi: November 14-18, 19 99]. Thanks are due to Professor J.B.G. Tilak and other participants for helpful com ments. In the same way, thanks are due to: the Department of Education, Government of Karn ataka (Bangalore) for sponsoring this research with full financial assistance under the ISEC's Project No.IX/QAU/10; participants of a seminar at ISEC for helpful comme nts and suggestions; and Mr Jayakrishna for technical assistance. However, the author is solely responsible for all views expressed here and any errors. According to the GIA code of Karnataka's collegiate education [as detailed in Murthy (1993: pp.217-244)], the basic objective of GIA is to encourage private enterprise in higher education or to total cost of providing collegiate education for the State government, especially as compared to a h ypothetical situation where all the aided colleges are to be totally established an d run as government colleges. Further, because of GIA, the teaching and non-teach ing staff is paid at par with the staff in government colleges, apart from equal serv ice conditions and benefits. Thus, private management can attract the best of qualifie d and experienced staff for their colleges, which, in the ultimate analysis, is a cri tical input for improving the quality of education or students' performance in the colleg es. 1. It might be added here that these policy issues are relevant at the national level as well. This is evident in discussions on the recomme ndations of the Report of the Committee of Funding of Institutions of Higher Educ ation [Chairman: Justice K. Punnayya: 1995] and All India Council of Technical Education's Report on Mobilisation of Additional Resources for Technical Education [Chairman: D. Swaminadhan: 1995]. See, for instance, Tilak (1995) for a summary of discussion on these reports in a seminar on Funding of Higher Education [January 23-24, 1995: National Institute of Educational Planning and Admi nistration (New Delhi)]. Further, the policy concerns are evident in discuss ions on Government of India's (1997) paper on Government Subsidies in India. 2. Up to 1986, Karnataka comprised only 19 districts. In 1986, Bangalore district was split into Bangalore Urban and Rural districts. Fro m 1996-97, seven new districts have been created. Thus, at present, Karnataka has 27 districts. For a recent inter-district comparison of levels of economic dev elopment, see Government of Karnataka (1999). 3. For a discussion of public financing of higher educ ation in developed countries, see Dolton et al (1997) for U.K. and Government of Onta rio (1996) for Canada. And, 4.

PAGE 28

28 of 34the papers in the symposium on economics of higher education, especially as they are related to USA, in Journal of Economic Perspect ives (Vol.13. No.1, 1999). For studies on developing countries in general, see Wor ld Bank (2000), and for specific countries, see World Bank (1997a) for China and Wor ld Bank (1997b) for Vietnam. This does not mean that studies on collegiate educa tion in India are ignorant of the role of GIA. This is evident in Mathew (1991) and A zad (1988). For instance, Azad (1988) provides with a comparison of GIA in four St ates (i.e. Andhra Pradesh, Gujarath, Haryana and Orissa), underlines the desir able objectives of GIA in terms of quantitative expansion and qualitative developme nt of colleges, and lists the criteria (i.e. equity, specificity, adequacy, elast icity, promotional, efficiency and administrative freedom) for evaluation of GIA. Howe ver, these studies do not assess the impact of GIA. 5. We are aware of alternative ways of assessing the i mpact of GIA on collegiate education. First, if the GIA is considered as a for m of public investment in higher education for generation of human capital, then the impact of GIA is defendable if the returns to it are positive and its continuation is defendable if the returns are positive and increasing over a period of time. For recent empirical studies on estimation of returns to investment in education, s ee Psacharopoulos and Mattson (1998) and Nevile and Saunders (1998). And, for an excellent global review of studies in returns to investment in education, see Psacharopoulos (1994). Second, impact of GIA in aided colleges may be assessed in comparison with students' performance in unaided private colleges and Governm ent colleges, provided that comparable data from both Government and private co lleges are available. In this case, GIA is defendable if students' performance in aided private colleges is higher than in unaided private colleges and Government col leges. Recently, Duraisamy and Subramanyam (1999) have done such a study for estim ating the factors affecting students' performance at higher secondary level, us ing sample survey data from Chennai (India). 6. For alternative estimation models for panel data, s ee, for instance, Chapter 2 and 3 in Hsiao (1995). 7. For a recent description of current status of colle giate education and GIA by districts in the State, see Narayana (1999). 8. A copy of the questionnaire is available from the a uthor upon request. 9. It should be emphasised that the number of permanen t staff included in the denominator for calculating STR in colleges refers to the number of full-time working staff, but not the number of sanctioned per manent full-time staff on GIA. If a sanctioned post is vacant due to factors, such as retirement or death or resignation, it may take sometime before it is fill up. In the m eanwhile, subject to the availability of workload and permission from the Government, one or two temporary staff may be appointed on GIA. Inclusion of these temporary s taff might have made little difference to STR for their number is considered to be negligible. 10. A reformulation of the FEM above is a Random Effect Model (REM) where intercept coefficients are considered to be random and unknown as given below. 11.

PAGE 29

29 of 34As compared to the formulation in (3), the REM abov e allows for the intercept to vary across colleges but not over time, such that t he variation is random as characterised by the random disturbance ( w I ) for the i-th observation. Given the standard assumptions, among others, on and between w i and e ij we may follow the two-step Generalised Least Square approach for esti mation of parameters in the REM above, as given in Hsiao [(1995), 32-38]. Furth er, following Green [(1997), Chapter 14], the presence of random effects [i.e. v ariance of the random effects, w I does not equal to zero] can be tested using a Lagra nge Multiplier (LM) test; and a choice between a FEM and REM (in terms of testing w hether or not the individual effects are uncorrelated with other regressors; if correlated the evidence is in favour of a FEM; if not, the evidence is in favour of a RE M) can be made using the Hausman's test based on the Wald criterion. Although a detailed analysis of the REM is beyond t he scope of this article, we report only the result of the LM test and Hausman's test. That is, the computed value of the LM statistic is 0.925. Since the 5 percent c ritical value from the Chi-square distribution with one degree of free is 3.842, the LM statistic is insignificant at 5 percent level. Thus, the evidence in favour of a ra ndom effect model is absent. On the other hand, Wald statistic for the Hausman's te st is 3.746. Since the 5 percent critical value from the Chi-squared distribution wi th 6 degrees of freedom is 11.07, the null-hypotheses that the individual/fixed effec ts are uncorreleted with the regressors (i.e. COM, COURSE, YGIA, STR AND RSFFY) is not rejected. Thus, on empirical grounds, the evidence is not in favour of the REM, or the FEM is preferable to the REM. One important reason for a reduction in the size of GIA is to contain the growth government deficit. For instance, as reported in RB I (1999), the revenue deficit of the Government of Karnataka has increased from Rs.7 8.9 crore during 1990-91 to Rs. 116.4 crore during 1993-94 and to Rs.151 crore during 1998-98 (BE). And, the GIA as a percentage of revenue deficits was 70 duri ng 1990-91, 75 during 1993-94 and 33 during 1997-98. From this view, the revenue deficit is substantially contributed by expenditure on the GIA over the year s. However, the recent decline in the share of GIA in revenue deficit can explaine d by the following policy changes in the GIA. First, all new colleges, started during or after 1987-88, have been allowed only on permanently non-GIA basis. Second, since 1991-92, no new courses have been sanctioned on GIA. These changes have red uced the expenditure on GIA. And, given the increasing size of absolute revenue deficit, the ratio of GIA to revenue deficit has come down since 1991-92. 12. Apart from the State government, the degree college s in Karnataka State are guided by the agencies below in regard to charging differe nt fee. First, the University, with which the college is affiliated, in regard to (i) r egistration fee; (ii) examination fee; and (iii) sports development fee. Second, the conce rned colleges in regard to students union; cultural activities; college magazi ne; and for issuing identity card of college/library. 13. For a discussion on private funding of higher educa tion in India, see Mathew (1996). 14. The issue of access to higher levels of education i n the context of private funding of education is recently raised in Mundle (1998: p.664 ). And, a framework for analysis of income distribution issues in financing educatio n is in Fernandez and Rogerson (1998). 15. A related paper in this regard is by Rothschild and White (1995) wherein an 16.

PAGE 30

30 of 34analytical framework is developed to financing high er education wherein students are considered not only as standard outputs but als o as inputs. This framework helps in relating students' fee to the amount of human ca pital received and in internalising the external effects of students on each other with in a class/college. ReferencesAzad, J.L. (1988). Higher Education in India: The Deepening Financial Crisis Radiant Publishers (New Delhi).Card, D. and Krueger, A.B. (1996). School Resources and Student Outcomes: An Overview of the Literature and New Evidence from No rth and South Carolina. Journal of Economic Perspectives 10 31-50. Darling-Hammond, L. (2000). Teacher Quality and Stu dent Achievement: A Review of State Policy Evidence. Education Policy Analysis Archives, 8 (1). (Available online: http://epaa.asu.edu/epaa/v8n1/) Dolton, P.J., Greenaway, D. and Vignoles, A. (1997) Whither Higher Education: An Economic Perspective for the Dearing Committee of I nquiry. The Economic Journal 107 710-726. Duraisamy, P. and Subramanyam, T.P. (1999). The rel ative effectiveness of public and private higher secondary schools in an urban centre in India. Journal of Educational Planning and Administration, XII 3752. Fernandez, R. and Rogerson, R. (1998). Public Educa tion and Income Distribution: A Dynamic Quantitative Evaluation of Education-Financ e Reform. American Economic Review, 88 813-833. Government of India. (1997). Government Subsidies i n India, Discussion Paper, Department of Economic Affairs, Ministry of Finance (New Delhi). Government of Karnataka. (1999). Human Development in Karnataka 1999, Planning Department (Bangalore).Government of Karnataka. (1998). District-wise and University-wise List of Government, Private (aided and unaided) and Law Colleges, Sta tistical Division, Department of Collegiate Education (Bangalore). Government of Karnataka. (1997). An Approach to Sub sidies in Karnataka, (Prepared by Plan Finance & Resource Division, Planning Departme nt), State Planning Board (Bangalore).Government of Ontario. (1996). Excellence, Accessib ility and Responsibility: Report of the Advisory Panel on Future Directions for Postsec ondary Education, Ministry of Education and Training (Toronto). Green, M. (1997). Econometric Analysis Englewood Cliffs, NJ: Prentice Hall.

PAGE 31

31 of 34Hanushek, E. A. (1996). Measuring Investment in Edu cation. Journal of Economic Perspectives, 10 9-30. Hsiao, C. (1995). Analysis of Panel Data Ny, NY: Cambridge University Press. Mathew, E.T. (1996). Financial Aspects of Privitisa tion of Higher Education. Economic and Political Weekly, XXXI 866-869. Mathew, E.T. (1991). Financing Higher Education: Sources and Uses of Fun ds of Private Colleges in Kerala New Delhi: Concept Publishing Company. Mundle, S. (1998). Financing Human Development: Som e Lessons from Advanced Asian Countries. World Development, 26 659-672. Murthy, G.V. (1993). Grants-in-Aid Code Bangalore, India: Lawyer's Law Book. Narayana, M.R. (1999). Grants-in-aid to collegiate education in Karnataka State: Current status and policy issues. Journal of Indian School of Political Economy, XI 295-319. Nevile, J.W. and Peter Saunders. (1998). Globalisat ion and the Return to Education in Australia. The Economic Record, 74 279-285. Padma, M.S. (1991). Research in Correlates of Achie vement: A Trend Report, in M.B. Buch. (Ed). Fourth Survey of Research in Education, 1983-1988 Vol.I, National Council of Educational Research and Training (New Delhi), 8 07-870. Psacharopoulos, G. and Mattson, R.. (1998). Estimat ing the Returns to Education: A Sensitivity Analysis of Methods and Sample Size. Journal of Educational Planning and Administration, XII 271-287. Psacharopoulos, G. (1994). Returns to investment in education: A global update. World Development, 22 1325-1343. RBI, Reserve Bank of India. (1999). Finances of State Governments: 1998-99 Supplement to RBI Bulletin February), LIII. Rothschild, M. and White, L.J. (1995). The Analytic s of the Pricing of Higher Education and Other Services in Which the Customers Are Input s. Journal of Political Economy, 103 573-586. Tilak, J.B.G. (1995). Funding Higher Education in I ndia. Economic and Political Weekly, XXX 426-429. World Bank. (2000). Higher Education in Developing Countries: Peril and Promise Washington, D.C.: The Task Force on Higher Educatio n and Society, The World Bank. World Bank. (1997a). China: Higher Education Reform, a World Bank countr y study Washington, D.C.: The World Bank. World Bank. (1997b). Vietnam: Education Financing, a World Bank country study

PAGE 32

32 of 34 Washington, D.C.: The World Bank. About the AuthorM. R. NarayanaProfessor of EconomicsInstitute for Social & Economic Change (ISEC)Nagarabhavi P.O. Bangalore 560 072, IndiaEmail: mrnarayana@yahoo.comCopyright 2001 by the Education Policy Analysis ArchivesThe World Wide Web address for the Education Policy Analysis Archives is epaa.asu.edu General questions about appropriateness of topics o r particular articles may be addressed to the Editor, Gene V Glass, glass@asu.edu or reach him at College of Education, Arizona State University, Tempe, AZ 8 5287-0211. (602-965-9644). The Commentary Editor is Casey D. C obb: casey.cobb@unh.edu .EPAA Editorial Board Michael W. Apple University of Wisconsin Greg Camilli Rutgers University John Covaleskie Northern Michigan University Alan Davis University of Colorado, Denver Sherman Dorn University of South Florida Mark E. Fetler California Commission on Teacher Credentialing Richard Garlikov hmwkhelp@scott.net Thomas F. Green Syracuse University Alison I. Griffith York University Arlen Gullickson Western Michigan University Ernest R. House University of Colorado Aimee Howley Ohio University Craig B. Howley Appalachia Educational Laboratory William Hunter University of Calgary Daniel Kalls Ume University Benjamin Levin University of Manitoba Thomas Mauhs-Pugh Green Mountain College Dewayne Matthews Western Interstate Commission for HigherEducation William McInerney Purdue University Mary McKeown-Moak MGT of America (Austin, TX)

PAGE 33

33 of 34 Les McLean University of Toronto Susan Bobbitt Nolen University of Washington Anne L. Pemberton apembert@pen.k12.va.us Hugh G. Petrie SUNY Buffalo Richard C. Richardson New York University Anthony G. Rud Jr. Purdue University Dennis Sayers Ann Leavenworth Centerfor Accelerated Learning Jay D. Scribner University of Texas at Austin Michael Scriven scriven@aol.com Robert E. Stake University of Illinois—UC Robert Stonehill U.S. Department of Education David D. Williams Brigham Young UniversityEPAA Spanish Language Editorial BoardAssociate Editor for Spanish Language Roberto Rodrguez Gmez Universidad Nacional Autnoma de Mxico roberto@servidor.unam.mx Adrin Acosta (Mxico) Universidad de Guadalajaraadrianacosta@compuserve.com J. Flix Angulo Rasco (Spain) Universidad de Cdizfelix.angulo@uca.es Teresa Bracho (Mxico) Centro de Investigacin y DocenciaEconmica-CIDEbracho dis1.cide.mx Alejandro Canales (Mxico) Universidad Nacional Autnoma deMxicocanalesa@servidor.unam.mx Ursula Casanova (U.S.A.) Arizona State Universitycasanova@asu.edu Jos Contreras Domingo Universitat de Barcelona Jose.Contreras@doe.d5.ub.es Erwin Epstein (U.S.A.) Loyola University of ChicagoEepstein@luc.edu Josu Gonzlez (U.S.A.) Arizona State Universityjosue@asu.edu Rollin Kent (Mxico)Departamento de InvestigacinEducativa-DIE/CINVESTAVrkent@gemtel.com.mx kentr@data.net.mx Mara Beatriz Luce (Brazil)Universidad Federal de Rio Grande do Sul-UFRGSlucemb@orion.ufrgs.brJavier Mendoza Rojas (Mxico)Universidad Nacional Autnoma deMxicojaviermr@servidor.unam.mxMarcela Mollis (Argentina)Universidad de Buenos Airesmmollis@filo.uba.ar Humberto Muoz Garca (Mxico) Universidad Nacional Autnoma deMxicohumberto@servidor.unam.mxAngel Ignacio Prez Gmez (Spain)Universidad de Mlagaaiperez@uma.es

PAGE 34

34 of 34 Daniel Schugurensky (Argentina-Canad)OISE/UT, Canadadschugurensky@oise.utoronto.ca Simon Schwartzman (Brazil)Fundao Instituto Brasileiro e Geografiae Estatstica simon@openlink.com.br Jurjo Torres Santom (Spain)Universidad de A Coruajurjo@udc.es Carlos Alberto Torres (U.S.A.)University of California, Los Angelestorres@gseisucla.edu


xml version 1.0 encoding UTF-8 standalone no
record xmlns http:www.loc.govMARC21slim xmlns:xsi http:www.w3.org2001XMLSchema-instance xsi:schemaLocation http:www.loc.govstandardsmarcxmlschemaMARC21slim.xsd
leader nam a22 u 4500
controlfield tag 008 c20019999azu 000 0 eng d
datafield ind1 8 ind2 024
subfield code a E11-00218
0 245
Educational policy analysis archives.
n Vol. 9, no. 21 (June 10, 2001).
260
Tempe, Ariz. :
b Arizona State University ;
Tampa, Fla. :
University of South Florida.
c June 10, 2001
505
Impact of grants-in-aid on collegiate education : evidence and implications of a regional study in India / M.R. Narayana.
650
Education
x Research
v Periodicals.
2 710
Arizona State University.
University of South Florida.
1 773
t Education Policy Analysis Archives (EPAA)
4 856
u http://digital.lib.usf.edu/?e11.218


xml version 1.0 encoding UTF-8 standalone no
mods:mods xmlns:mods http:www.loc.govmodsv3 xmlns:xsi http:www.w3.org2001XMLSchema-instance xsi:schemaLocation http:www.loc.govmodsv3mods-3-1.xsd
mods:relatedItem type host
mods:identifier issn 1068-2341mods:part
mods:detail volume mods:number 9issue 21series Year mods:caption 20012001Month June6Day 1010mods:originInfo mods:dateIssued iso8601 2001-06-10