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Primary school attendance in Honduras
Arjun S. Bedia,*, Jeffery H. Marshallb
a Institute of Social Studies, Kortenaerkade 12, 2518 AX, Den Haag, NetherlandsbStanford University, Palo Alto, CA, USA
Received 1 August 2000; accepted 1 September 2001
Abstract
Honduras has recorded impressive gains in expanding educational access in the 1990s, with the
result that primary education is available to almost all children. With improved access, the focus has
shifted to quality and efficiency issues. Previous research suggests that academic achievement is still
quite low, while repetition and school desertion rates continue to remain high. An important cause of
these outcomes appears to lie in patterns of school attendance. Low levels of school attendance may
be responsible for low academic achievement, which, in turn, is linked to high repetition and
desertion rates. Recognizing this probable chain of events, this paper focuses on the school
attendance decision. We rely on recently collected data from a national sample of Honduran primary
schools to specify and estimate a model of school attendance. We find that increases in the expected
benefits of attending school exert a strong impact on the school attendance decision.
D 2002 Elsevier Science B.V. All rights reserved.
JEL classification: D1; I2
Keywords: Primary school; Attendance; Honduras; School inputs; Supply of schooling
1. Introduction
Investments in education are widely recognized as a key component of a country’s
development strategy. Increases in the quantity and quality of educational provision have
been associated with a wide range of benefits including enhanced productivity, reduced
poverty and income inequality, improved health and economic growth.1 Spurred by such
0304-3878/02/$ - see front matter D 2002 Elsevier Science B.V. All rights reserved.
PII: S0304 -3878 (02 )00056 -1
* Corresponding author. Tel.: +31-70-4260493; fax: +31-70-4260799.
E-mail addresses: [email protected] (A.S. Bedi), [email protected] (J.H. Marshall).
www.elsevier.com/locate/econbase
1 See Lockheed and Associates (1991) for a detailed review.
Journal of Development Economics 69 (2002) 129–153
evidence, governments in developing countries devote a substantial fraction of their total
expenditure to the education sector.2
Honduras is no exception, as successive governments have invested substantial
resources in education. Between 1993 and 1996, public expenditure on education
accounted for 16.5% of total government outlays (UNDP, 1999). These investments have
expanded coverage and access at all levels and, as a result, the gross enrollment ratio for
Hondurans aged 6–23 (in primary, secondary and tertiary education) has risen from 47%
in 1980 to 60% in 1995 (UNESCO, 1999).3 The expansion in educational opportunities
has been especially notable in the pre-primary and primary sectors, and recent initiatives
have targeted the most needy populations in Honduras.4
However, these impressive gains in coverage have been tempered somewhat by low
levels of academic achievement and high rates of grade repetition and desertion. A recent
national application of criterion-referenced Spanish and Mathematics exams resulted in
national averages in Grade 3 of 39.7% and 35.9% in Spanish and Mathematics,
respectively (UMCE, 1998).5 In 1996, official grade repetition rates were 19.4% in
Grade 1, 11.6% in Grade 2 and 8.6% in Grade 3, although real rates are likely to be even
higher (Van Steenwyck, 1997; Marshall, 2000). Although difficult to calculate, the World
Bank (1995) estimates that about 5.0% of Honduran primary school students desert
annually.
While part of the reason for low achievement and consequently high repetition and
desertion rates may lie in student ability, it is likely that such outcomes are largely driven
by other factors. In a review of the Honduran education system, the World Bank identified
low attendance rates and poor school inputs as the two main factors responsible for high
repetition rates, which, in turn, was identified as the most important cause of the high
dropout rate (World Bank, 1995).
The economic contribution of children to families in developing countries (especially in
rural areas) and accordingly the opportunity cost associated with school attendance may be
substantial. Attendance will suffer when parents perceive that the return associated with
2 According to UNDP (1999), between 1993 and 1996, the average (unweighted) expenditure on education
as a percentage of total government expenditure for developing countries was 14.8%.3 Gross enrollment ratios at the primary and secondary level were 112% and 32%, respectively. For a more
detailed overview of Honduran educational coverage, see Edwards (1995), Edwards et al. (1996) and Van
Steenwyck and Mejia (1996).4 Examples include the expansion of community-based preschools (Centros Comunitarios de Iniciacion
Escolar—CCIEs) that are designed to reach rural populations (World Bank, 1995) and the recent creation of 500
community-based primary schools (Proyecto Hondureno de Educacion Comunitaria—PROHECO) based on the
EDUCO (Educacion con Participacion de la Comunidad) program in El Salvador.5 The UMCE exams are designed to measure the implemented curriculum and are not intended for pass/fail
decisions, so deciding on a cutoff point for passing and failing is an inherently arbitrary exercise. Nevertheless,
the exams do pretend to measure ‘‘mastery’’ for each curriculum component that is covered, which usually
include three questions per component. Students who can answer at least two of the three questions correctly are
considered to have mastered the component. These aggregated averages show that few Honduran primary
students are mastering a significant portion of the curriculum, according to the UMCE standards. Furthermore,
since the UMCE exams comprise multiple-choice questions with four options, averages below 40% are indicative
of low levels of achievement.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153130
time spent in school does not justify the loss of a child’s economic contribution. Parental
perceptions of school inputs may also affect the attendance cost–benefit calculus as low-
quality teachers or limited availability of teaching materials may attenuate the expected
benefits from attending school. A reduction in days attended probably exerts a negative
influence on academic achievement and increases the probability of repetition and
desertion. There may also be a more direct link between school attendance and repetition
as some school systems require minimum levels of attendance before allowing a student to
appear for exams (see Jacoby, 1994).
Recognition of these indirect and direct links between school attendance and educa-
tional outcomes suggests that a focus on the factors underlying the school attendance
decision itself may be quite useful in understanding the dynamics of human capital
formation in a developing country. While there is a substantial amount of literature that has
examined the determinants of school enrollment, test scores, grade repetition and
desertion, there is limited work on the factors that motivate school attendance (for a
review, see Strauss and Thomas, 1995).6 A handful of authors have included a measure of
school attendance as an explanatory variable in educational production functions. One
example is Tan et al. (1997), who use data from the Philippines and find that the number of
days missed has a negative and statistically significant effect on Mathematics test scores.
Fuller et al. (1999) also include this variable as a regressor in their analysis of the
determinants of academic achievement in Brazil, although the point estimates are not
significant. While including attendance as an explanatory variable does highlight the
influence of attendance on test scores, it ignores the potential endogeneity of school
attendance and achievement and does not permit an analysis of the factors that determine
school attendance.7
This paper builds on our earlier work (Bedi and Marshall, 1999) and focuses primarily
on the school attendance decision. We use nationally representative data collected by the
External Unit for the Measurement of School Quality (Unidad Externa de Medicion de la
Calidad de la Educacion—UMCE) in Honduras to specify and estimate a model of
primary school attendance. We assume that parents determine the particular pattern of
school attendance for their children on the basis of expected gains and the costs of
attending school. We proceed in two steps. First, we estimate the effect of child, family and
school characteristics on test scores and obtain predicted test scores. In the second step, we
estimate a school attendance model that includes predicted test scores as a measure of the
expected gains of school attendance. This paper improves on our earlier work in two ways.
First, the UMCE database includes a nationally representative sample of primary schools,
while our earlier work was based on a limited sample drawn from one province of rural
Honduras, which limited the generalizability of our results. Second, the measure of school
attendance that we use in this paper allows a decomposition of school attendance into
6 Enrolling in school is clearly the first step before one may begin to examine patterns of school attendance.
In the Honduran context, where there is almost universal enrollment, the important issue is not whether a child is
enrolled in school but how often does a child attend school.7 Although the main aim of their paper is to compare test scores across school types, Jimenez and Sawada
(1999) do provide estimates of school attendance regressions that allow them to examine the determinants of
attendance as well as make comparisons across school types.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 131
demand and supply components. This feature of the data is discussed in a subsequent
section.
Section 2 introduces the analytical framework that we use to motivate our empirical
work. Section 3 describes the data and the variables used in the analysis. Section 4
presents results and Section 5 concludes.
2. Costs, benefits and school attendance—an analytical framework
School attendance patterns in developing countries vary substantially across house-
holds. Some children may never enter school, while others may attend only part time. The
degree of part-time schooling may vary from missing a few weeks to missing several
months. The variation in attendance patterns suggests that parents evaluate differently the
costs and benefits of attending school and that this evaluation for the same household may
also vary according to the particular time of the year. For instance, during the harvest
season, the opportunity costs of attending school may far outweigh the benefits, resulting
in temporary withdrawal, while at other times, the benefits may outweigh the costs and
result in regular school attendance.8 Thus, school attendance over the year may be viewed
as the consequence of a daily household decision where a child attends school on a
particular day if the expected benefits from attending school on that day are greater than
the associated costs.
To formalize these notions and to motivate our empirical work this section presents a
framework tailored to our needs.9 Consider that the school year consists of n days, and it is
Day i of the school year. We assume that each household has a utility function defined over
bi and ci, where bi denotes the benefits associated with attending school on Day i, and ci is
household consumption on Day i. While attending school yields benefits, it comes at a
cost. Direct and opportunity costs associated with school attendance lower resources
available for household consumption. Accordingly, household utility on Day i conditional
on school attendance (denoted by subscript 1) is given as
Ui1 ¼ Uðbi; ci1Þ: ð1Þ
The associated budget constraint is
yi ¼ ci1 þ pi; ð2Þ
where yi is household income and pi represents the total cost associated with school
attendance.
8 This is especially true in rural Honduras, where children may drop out of school for several months during
the harvest season only to return the next year. See World Bank (1995, p. 9). School attendance patterns in our
data are discussed later on in the text.9 The framework used here is similar to those in Gertler and Van Der Gaag (1988) and Gertler and Glewwe
(1990).
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153132
In a similar fashion, the utility associated with not attending school may be defined
by
Ui0 ¼ Uðci0Þ: ð3Þ
The budget constraint is yi = ci0. Given the utility associated with both options,
households choose the option that yields the highest utility. The solution to the daily
unconditional utility maximizing problem is
Ui* ¼ maxðUi1;Ui0Þ; ð4Þ
where Ui* is the maximum utility. Alternatively, school attendance may be defined in
terms of a dichotomous variable, ai, where ai = 1 if a child attends school and 0
otherwise. A child attends school, i.e., ai = 1 if Ui1>Ui0. Summing up the outcomes of
these daily decisions, over the school year, leads to the observed pattern of school
attendance.
2.1. Empirical specification
Since our purpose is to empirically explore the role of expected gains and costs on the
school attendance decision, we proceed by specifying linear forms of the conditional
utility function. For the schooling option,
Ui1 ¼ b1bi þ b2ci1 þ ei1 ð5Þ
where the b’s are coefficients to be estimated and ei1 is assumed to be a mean zero,
normally distributed error term with positive variance. Since ci1 = yi� pi, we may rewrite
Eq. (5) to obtain
Ui1 ¼ b1bi þ b2ðyi � piÞ þ ei1 ð6Þ
The utility function for the nonschooling option is
Ui0 ¼ b2yi þ ei0 ð7Þ
Thus, an individual attends school, i.e., ai= 1 if b1bi� b2pi + ei1� ei0>0.The chances of attending school on a particular day may be expressed in terms of a
linear probability model that may be written as
ai ¼ b1bi � b2pi þ eia; ð8Þ
where eia is a normally distributed, mean zero, positive variance composite error
term.10
10 In this linear utility specification, income has been differenced out of the decision rule and does not
directly affect the school attendance decision. Household endowments are assumed to influence the school
attendance decision through opportunity costs.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 133
Eq. (8) depicts the probability of attending school on any particular day. Since we are
interested in the yearly pattern of school attendance, we may sum up the outcome of the
daily attendance decision over the course of the school year,
Xn
i¼1
ai ¼Xn
i¼1
ðb1bi � b2pi þ eiaÞ ð9Þ
to yield
A ¼ b1Bþ b2P þ eA; ð10Þ
where yearly school attendance, A, depends on B, the expected benefits associated with
school attendance over the school year, and P, the yearly costs of attending school.
2.2. Costs of attending school
The total cost (P) of sending a child to school includes monetary (direct) and indirect or
opportunity costs. Since education is largely subsidized the main cost incurred by
households is likely to be in the form of opportunity costs. Attending school reduces a
child’s availability for work in and outside the home. If a child makes substantial
contributions to family income, or plays an important role in supporting other working
members, then the opportunity cost of attending school is likely to be high and this may
curtail the attractiveness of the schooling option.11
Both of these cost components are likely to differ across households. For instance,
direct costs may vary due to differences in transportation costs. Opportunity costs and the
value of a child’s time may also differ due to personal characteristics of the child (age, sex)
and the value that parents place on a child’s time. Since we do not directly observe the
costs of attending school we allow P to depend on a vector of child, family and other
characteristics that capture the cost of attending school.
2.3. Benefits of attending school
Parents have to ascertain the total benefits (B) associated with school attendance. We
consider two types of benefits that may influence parental decision making. The main
benefit associated with attending school is likely to be the expected addition to a child’s
human capital. To capture this effect, we need a measure of the human capital gains
associated with school attendance. For this study, we incorporate a measure that is widely
used to indicate the benefits derived from education: test scores. However, using actual test
scores is obviously incorrect due to the potential endogeneity between test scores and
11 For example, Patrinos and Psacharopoulos (1995) show that child earnings account for 27.8% of total
income in urban households in Paraguay, while Patrinos and Psacharopoulos (1997) show that child labor
contributes 17.7% of household income in rural Peru. A number of studies have also demonstrated that the
presence of younger siblings in the household may affect educational outcomes. Using Honduran household
survey data, Edwards et al. (1996) show that children are likely to delay initial enrollment, and attain fewer years
of education, when an infant sibling is present in the home.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153134
attendance. In order to derive an appropriate measure of human capital gains, we proceed
by estimating educational production functions, one for each subject, for those students for
whom test score data are available. These test score equations are specified as
H ¼ dZ þ eH ; ð11Þ
where H is a measure of human capital or in this case test scores, Z is a vector of
individual, family and school characteristics that influence H and eH is an error term.
Estimates from the educational production functions are used to predict test sores for each
individual. These predicted values (H) are included in Eq. (10) in order to capture the
human capital benefits associated with attending school.
In addition to school characteristics that have an impact on test scores, there may be
other school characteristics that do not affect academic achievement but do signal the
quality (Q) of a school and directly influence the benefits that parents attribute to school
attendance. For instance, whether a school has a telephone connection or a sports field may
not directly influence academic achievement. However, these are easily observed signals
that may be used by parents to judge the quality of a school and, in turn, may directly
influence the benefits that parents associate with school attendance. Thus, some school
inputs and facilities may directly influence parental evaluation of the benefits associated
with school attendance, while others may exert an influence on benefits through their
impact on test scores.
To account for the different kinds of benefits that parents may associate with school
attendance, Eq. (10) may be adjusted to accommodate both the expected human capital
benefits (H) and direct benefits (Q) and may be rewritten as
A ¼ b1H H þ b2QQþ b3P þ eA; ð12Þ
where b1H is a coefficient to be estimated and b2Q and b3 are conformable coefficient
vectors to be estimated. As this equation depicts, school attendance is treated as a function
of expected human capital benefits, other benefits and costs.
3. Data description and specification
The data used in this paper are drawn from the second national application of
standardized tests administered by the UMCE in October 1998 and March 1999.12 The
sample includes 586 schools from 17 of 18 states13 (departamentos) and represents
approximately 7% of Honduran primary schools. In this application, Spanish and
Mathematics tests were administered to students in Grades 2 and 4. In addition, second
and fourth grade teachers were administered questionnaires, as were school directors in
12 The two primary functions of the UMCE are to develop and apply standardized tests covering the basic
learning objectives and study the factors associated with academic achievement, especially in student cohorts. See
UMCE (1998) and World Bank (1995) for descriptions of the project.13 Gracias a Dios, an extremely isolated state in eastern Honduras, was not included in the sample due to the
relatively small number of schools and students in this region and the difficulty of school access.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 135
each school. Test administration personnel filled out observation instruments in each
school detailing variables such as school type, enrollment, days worked, school character-
istics (including materials and hardware) and special programs. They also copied student
data including days missed during the school year, work attitudes and Spanish and
Mathematics grades from teacher grade books in second and fourth grades. Finally, parents
with children in second or fourth grades were interviewed to collect data on parental
characteristics such as education and work experiences, attitudes towards education and
specific problems in their school, among other variables. Further details on the data are
available in UMCE (1999).
In this paper, we restrict our analysis to students in second and fourth grade for whom
we have complete information on test scores, attendance, child, family and school
characteristics. These restrictions result in sample sizes of 7210 for Grade 2 Spanish
and 6938 for Grade 2 Mathematics. The Grade 2 attendance equation is estimated over a
sample of 6139 observations. For Grade 4, the sample sizes are 5359 for Spanish, 5024 for
Mathematics and 4501 for the attendance equation.14 Descriptive statistics and variable
definitions by grade are provided in Tables 1 and 2.
Turning to the empirical implementation, two educational production functions—one
for each subject—are estimated for each grade, yielding a total of four equations. The
dependent variables (H) are standardized test scores on Spanish and Mathematics
examinations. The independent variables are classified into child, family, teacher and
classroom/school characteristics. The child-specific variables include age and sex, as well
as an indicator of whether Spanish or Mathematics is a child’s favorite subject among the
four main subjects that also include sciences and social studies. This variable is included to
control for the effect that inclination towards a particular subject may have on test scores.
Family characteristics include variables that reflect parental attitudes towards education
such as whether a child attended preschool, whether parents help children with their
homework and parental participation in school activities. Household resources are
measured by mean years of education of the parents and an index of household wealth
(see Table 1 for details).
Several variables are included to control for the quality of instruction received by the
child. An instructor’s knowledge of the subject is captured by years of education, years of
experience, the number of teaching seminars attended and test scores on Spanish and
Mathematics examinations. The test score variable is expected to be a more accurate and
current measure of an instructor’s knowledge. In an attempt to control for unobserved
teaching attributes and skills, our regressions include a self-reported measure of teacher’s
self-confidence. Class characteristics include the size of the class, an indicator of whether
several grades are taught simultaneously in the same grade (i.e., a multigrade classroom),
and the availability of textbooks.
The dependent variable (A) in the school attendance Eq. (12) is the number of days that
a child attends school during the school year. This measure is created by subtracting the
number of days that a child misses school from the number of days the school was in
14 The number of observations available for estimating the attendance equation estimations drops, because in
some schools, we have data on children (including test scores), parents, teachers and schools, but the teacher
grade books were not available and, therefore, it was not possible to construct the attendance variable.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153136
Table 1
Variable definitions and descriptive statistics (Grade 2)
Variable Observations Mean Standard deviation
Child characteristics
Spanish test score 7210 35.22 15.989
Mathematics test score 6938 43.22 17.819
Age 7210 8.967 1.402
Female = 1 7210 0.504 0.500
Favorite subject—Spanish = 1 7210 0.289 0.453
Favorite subject—Mathematics = 1 6938 0.425 0.494
Family characteristics
Attended preschool = 1 7210 0.595 0.491
Receives parental help = 1 7210 0.313 0.463
Father’s educational attainment in yearsa 1844 4.635 4.142
Mother’s educational attainment in years 2007 4.661 3.753
Parents active in school = 1b 7210 0.150 0.357
Index of household wealthc 7210 3.031 2.124
Teacher characteristics
Years of education 7210 12.563 0.982
Years of experience 7210 12.007 8.088
Seminars attended 7210 0.957 1.358
Test score—Spanish 7210 80.84 0.121
Test score—Mathematics 6938 51.37 0.190
Index of self-confidenced 7210 4.154 0.536
Classroom/school characteristics
Multigrade classroom= 1 7210 0.347 0.476
Adequate supply of Spanish texts = 1 7210 0.283 0.448
Adequate supply of Mathematics texts = 1 6938 0.434 0.493
Class size 7210 40.35 12.25
Time taken to reach school 6139 17.44 16.43
Lunch program= 1 6139 0.056 0.300
Telephone connection = 1 6139 0.208 0.406
Electricity connection = 1 6139 0.592 0.491
Index of other school facilitiese 6139 4.078 1.713
a For a large number of observations, we were unable to obtain information on parental education. To retain
these observations, we assigned a value of zero to parental education. Our regressions include a dummy variable
to indicate such observations.b This variable is based on teacher evaluation of parental participation in school. The variable is coded as 1 if
parents are highly active in school and 0 otherwise.c Parental wealth is constructed using presence in the house of: a television, a refrigerator, an automobile,
electricity, a telephone, indoor plumbing and a nondirt floor.d Self-confidence index is constructed using teacher responses to 9 statements that ask them to rank their
response on a scale of 1 = Strongly Disagree to 5 = Strongly Agree. For example, the statements refer to teaching
ability (‘‘I am qualified to teach the subjects’’), teaching impacts on students (‘‘I have a strong influence on the
academic achievement of my students’’) and happiness with the teaching profession (‘‘If I had to choose again I
would become a teacher’’).e The school facilities include bathrooms, administrative office, kitchen, pantry, laboratory, athletic field,
library and garden.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 137
Table 2
Variable definitions and descriptive statistics (Grade 4)
Variable Observations Mean Standard deviation
Child characteristics
Spanish test score 5359 39.39 15.450
Mathematics test score 5024 32.02 11.195
Age 5359 10.85 1.435
Female = 1 5359 0.531 0.499
Favorite subject—Spanish = 1 5359 0.208 0.406
Favorite subject—Mathematics = 1 5024 0.401 0.490
Family characteristics
Attended preschool = 1 5359 0.573 0.494
Receives parental help = 1 5359 0.385 0.486
Father’s educational attainment in yearsa 2157 4.969 4.358
Mother’s educational attainment in years 2335 4.976 4.058
Parents active in school = 1b 5359 0.140 0.346
Index of household wealthc 5359 3.387 2.181
Teacher characteristics
Years of education 5359 12.653 1.081
Years of experience 5359 13.288 8.116
Seminars attended 5359 1.203 1.736
Test score—Spanish 5359 79.41 12.52
Test score—Mathematics 5024 49.43 15.69
Index of self-confidenced 5359 4.149 0.482
Classroom/school characteristics
Multigrade classroom= 1 5024 0.396 0.489
Adequate supply of Spanish texts = 1 5359 0.346 0.475
Adequate supply of Mathematics texts = 1 5024 0.412 0.492
Class size 5359 38.30 10.51
Time taken to reach school 4501 15.88 14.31
Lunch program= 1 4501 0.050 0.217
Telephone connection = 1 4501 0.202 0.401
Electricity connection = 1 4501 0.590 0.492
Index of other school facilitiese 4501 4.118 1.728
a For a large number of observations, we were unable to obtain information on parental education. To retain
these observations, we assigned a value of zero to parental education. Our regressions include a dummy variable
to indicate such observations.b This variable is based on teacher evaluation of parental participation in school. The variable is coded as 1 if
parents are highly active in school and 0 otherwise.c Parental wealth is constructed using presence in the house of: a television, a refrigerator, an automobile,
electricity, a telephone, indoor plumbing and a nondirt floor.d Self-confidence index is constructed using teacher responses to 9 statements that ask them to rank their
response on a scale of 1 = Strongly Disagree to 5 = Strongly Agree. For example, the statements refer to teaching
ability (‘‘I am qualified to teach the subjects’’), teaching impacts on students (‘‘I have a strong influence on the
academic achievement of my students’’) and happiness with the teaching profession (‘‘If I had to choose again I
would become a teacher’’).e The school facilities include bathrooms, administrative office, kitchen, pantry, laboratory, athletic field,
library and garden.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153138
operation during the 1998 school year. A detailed analysis of this variable is provided in
Section 4. Attendance is specified as a function of the benefits and costs associated with
schooling. Benefits are represented by the expected human capital gains from schooling, H
(obtained from the production function estimates), and by school facilities that signal the
quality (Q) of the school and from which parents may directly derive benefits. The
specific school facility variables include the presence of a telephone connection, an
electricity connection and a composite variable that sums other school facilities that a
school may possess. Since we do not have any direct measures of opportunity costs (such
as child wages), we specify opportunity costs (P) as a function of child and family
characteristics. The child characteristics include the age and sex of the child. Variation in
parental evaluation of child time is controlled by the same set of family characteristics that
are included in the educational production functions. School related characteristics that
may influence the cost of school attendance are the time taken to get to school and whether
the school has a lunch program.
Before turning to the results, a number of econometric issues must be dealt with. First,
the educational production functions are estimated using data only on those students who
attended school on the day that the tests were administered. Using data only on test takers
may result in inconsistent estimates, since children who are not in attendance on the day of
the test may not have the same characteristics as those who were in school on the day of
the test.15 To account for this source of bias, we estimate selection-corrected educational
production functions.16
Another concern while estimating educational production functions is the potential
endogeneity of school inputs. If parents migrate in response to differences in school inputs,
or if educational planners distribute school inputs to compensate for low student achieve-
ment, then estimates of the effect of school input characteristics may be biased.
Endogeneity due to parental migration appears to be quite unlikely in the Honduran
context. Analysis of household survey data indicates that 90% of individuals migrate in
order to find work and the remaining migrate for family reasons (see Bedi, 1997).
Endogeneity due to the second source is quite possible. However, examination of our data
does not reveal any clear and consistent pattern between the distribution of school
resources and the general economic characteristics of a region. For instance, in Grade 2,
16 While we have fairly complete information on 7210 individuals for Grade 2 Spanish and 6938 for Grade 2
mathematics, there are around 4500 additional students enrolled in Grade 2 who did not take the exam. The
selection-corrected specifications are estimated over this larger sample. We lose some of these observations since
we do not have complete information on all of the explanatory variables. The selection correction estimates are
based on sample sizes of 10,054 and 9985 for Grade 2 Spanish and Grade 2 mathematics, respectively. In Grade
4, there are around 3000 students who did not attend school on the day of the exam. Here, we also lose some
observations due to missing information on the explanatory variables and the selection corrected estimates for
Grade 4 Spanish and mathematics are estimated over sample sizes of 7220 and 7078, respectively.
15 There are other potential sources of selection bias that may have a bearing on estimates of the academic
achievement equations. For instance, children may never enroll in school or may drop out of school before
reaching Grade 2/Grade 4 and, thus, those who do enroll and do reach these grades may be regarded as a
selective cohort of students. Since almost all children enroll in school, any selection bias from this source is
likely to be small. However, since a large number of students do leave the school system before reaching Grade
2/Grade 4, our analysis should be viewed as conditional and restricted to those individuals who have reached
Grade 2/Grade 4.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 139
schools in metropolitan areas have slightly larger class sizes (approximately 40 students)
as compared to schools in towns (around 38 students), however, test scores of teachers is
slightly higher in metropolitan schools (85 versus 81%).17
Finally, the school-specific nature of our data raises the possibility that students
attending the same school (i.e., sharing the same observable characteristic) may also
share the same unobservable characteristics, which may lead to the presence of intraschool
error correlation (see Moulton, 1986). Although least squares is still consistent, the
presence of these effects results in biased standard errors and consequently misleading
statistical inference. To account for this, an appropriate robust variance–covariance matrix
is computed, and the reported t statistics for our various estimates are based on this
adjusted matrix.
4. Results
The results are divided into three sections. In Section 4.1, we examine patterns of
school attendance and present a decomposition of attendance into demand and supply side
components. Section 4.2 discusses the determinants of academic achievement in Math-
ematics and Spanish, while Section 4.3 presents estimates of the school attendance
equation.
4.1. School attendance patterns
The total number of days that a child attends school is determined by parental or child
demand for schooling and the supply of schooling. While a decomposition of the days
missed due to demand and supply factors does not affect the basic notion that school
attendance is important in determining educational outcomes, identifying whether a child
misses school due to demand or supply factors is important from a policy perspective. If
the main problem is one of low demand for schooling, then the appropriate response may
be policies designed to lower costs of schooling or a policy of enhanced investments in
school inputs to increase the expected returns from schooling. On the other hand, limited
supply of schooling would suggest another set of policy responses.
An important feature of the data used in this paper is that we have information not only
on the number of days that each student missed during the 1998 school year, but also on
the number of days that each school in the UMCE sample was open during the school
year.18 This information combined with our knowledge of the number of days that a school
18 This additional information was collected as a consequence of our initial investigation into this issue when
we were forced to assume that each school remained open for 160 days and the entire school attendance issue was
treated as a demand side problem. As the data used in this study clearly demonstrate, this is an unrealistic
assumption, especially for a nationally representative sample of primary schools.
17 Notwithstanding these patterns, it is possible that the distribution of school inputs and student achievement
are systematically related. Due to lack of suitable data, we are unable to use an instrumental variables (IV)
approach. However, we are able to provide some clues on the direction of the potential bias by referring to our
earlier work (Bedi and Marshall, 1999). In our previous paper, we found that the coefficients on the school inputs
in IV regressions were systematically larger (in absolute terms) than the corresponding OLS estimates.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153140
is expected to remain open helps us identify whether a child misses school due to lack of
demand for schooling or due to lack of school supply. In terms of an equation, Dm, the
days missed may be decomposed into
Dm ¼ ðDo � DaÞ þ ð172� DoÞ; ð13Þ
where Do is the number of days that school is offered and Da represents days attended. The
first term in parentheses on the right-hand side represents days missed due to lack of
demand for schooling. School is offered on those days, but parents do not send their
children to school. The second term represents days missed due to lack of school supply.
Schools are meant to be operating 172 days during the school year, and the gap between
the expected days of operation and the days that a school is actually offered represents
days missed due to lack of supply.19
The patterns of school attendance and a demand–supply decomposition of days missed
for students in Grade 2 and Grade 4 are displayed in Table 3a and b. On average, a child
attends 143–144 days of school, which translates into a loss of around 5 weeks of
schooling. The number of days attended varies from 121 at the 10th percentile to 161 at
the 90th percentile for Grade 2 and 124 and 162 for the same percentiles in Grade 4, i.e., a
range of about 1.5–9.5 weeks of missed classes.20
Of particular interest to the present analysis is the decomposition of days missed into
demand–supply components. This decomposition on the basis of Eq. (13) is displayed in
Table 3a and b. For Grade 2, at the mean, the 29 missed days may be decomposed into 10
days missed due to lack of demand for schooling and 19 days missed due to lack of supply.
A similar pattern prevails for Grade 4, with 9 days accounted for by lack of demand and 19
days missed due to lack of supply. For both grades, the decomposition at the mean or at
different points of the distribution clearly indicates that while both demand and supply
20 An immediate question that arises is whether these missed days translate into lower levels of human capital
or are students are able to make up despite missing school? Although educational achievement and school
attendance are endogenous, to establish the effect of school attendance on educational outcomes, we estimated
educational production functions for both subjects and both grades that included the number of days attended as a
regressor. For all four regressions, we found that the number of days attended had a positive impact on test scores
and was statistically significant. For Grade 2, the point estimates indicated that an increase in school attendance
by one standard deviation (14 days) would increase educational achievement by 3.1–4.4%. For Grade 4, the
corresponding calculation yielded increases of 2.2–4.4%. A detailed examination of the effect of attendance on
test scores is available in Marshall and White (2000).
19 This decomposition may lead to an exaggeration of the supply side of the problem. If parental (lack of)
demand for schooling on a particular day coincides with a day that school is not offered, it will lead to an
overemphasis of the supply side of the problem. Except for noting this possibility, we are not able to offer any
additional information on the extent of such an exaggeration. It is also possible that the lack of supply may
dissuade parents from sending their children to school. If this is the case, then the decomposition presented here
would underestimate the true extent of the supply side problem. Our data show that there is a positive correlation
(0.18 for Grade 2 and 0.13 for Grade 4) between student absences and the number of days that a school is closed.
Exploratory regressions of days that a student is absent on days that a school is closed (controlling for other
characteristics) provide some support for a positive relationship between these two variables. However, the
statistical significance of the relationship is sensitive to the inclusion of provincial controls. Detailed results are
available.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 141
factors are responsible for limiting school attendance a larger share of the problem
(between 60% and 71%) may be attributed to lack of school supply.
Due to limited information on the supply side, the primary focus of this paper is on
factors that inhibit attendance from the demand side. Although our data are not particularly
well suited in terms of analyzing the supply side, some clues may be gleaned from the
information that we have. First, variation in the supply of schooling may be associated with
the type of school administration. While most schools in Honduras are publicly provided
and administered, there are a small number of schools that are run privately. As shown in
Table 4 (rows 1 and 3), there are 24 private schools in our sample, and on average, private
schools offer 2 more weeks of schooling as compared to public schools. At first glance, this
would suggest that the type of school administration plays a key role in determining the
supply of schooling. However, conditioning on the location of the schools (rural or urban)
suggests that the differences in supply of schooling have more to do with the location of the
school rather than the school administration (Table 4, rows 2, 4, rows 2, 4, 5 and 6).
Differences in the supply of schooling appear to be more pronounced across location than
Table 3
School attendance—a decomposition
Statistic Days school
open
Days
attended
Days missed
demandaDays missed
supplybTotal days
missed
(a) Grade 2
Mean (standard deviation) 153 (10.91) 143 (15.73) 10 (9.53) 19 29
Percentiles
10 138 121 17 34 51
20 145 131 14 27 41
30 148 137 11 24 35
40 152 142 10 20 30
50 155 145 10 17 27
60 157 149 8 15 23
70 159 153 6 13 19
80 162 156 6 10 16
90 165 161 4 7 11
(b) Grade 4
Mean (standard deviation) 153 (11.14) 145 (15.21) 9 (8.93) 19 28
Percentiles
10 139 124 15 33 48
20 145 134 11 27 38
30 148 139 9 24 33
40 153 144 9 19 28
50 155 147 8 17 25
60 158 151 7 14 21
70 160 154 6 12 18
80 163 157 6 9 15
90 166 162 4 6 10
a Days missed due to lack of demand for schooling is computed by subtracting days attended from the days
that a school was open.b Days missed due to lack of school supply is computed by subtracting the days that a school is open from the
official length of the school year (172 days).
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153142
across school types. As displayed in Table 4, urban private schools offer 5 more days of
schooling than urban public schools, while urban public schools offer 11 more days of
schooling than rural public schools. Turning to another dimension, Table 4 also presents the
mean supply of schooling by the kind of teacher resources available in a school. Schools
with multiple teachers offer around 9 more days of schooling as compared to schools with a
single teacher. An additional factor that may be related to the supply of schooling is the
distance of the school from the state capital. It is possible that remote schools are less likely
to remain open as compared to schools located closer to state capitals.
To examine the relative impact of these various factors, we present OLS estimates from
regressions of the days a school is open on variables that represent the type and location of
a school. These estimates are presented in Table A1 in Appendix A. As suggested by the
foregoing discussion, the estimates show that (see column 2) the type of administration is
not as important in determining school supply as compared to some of the other factors.
Limited teacher resources are clearly associated with reduced supply of schooling. The
location of a school appears to be particularly important. Schools located far away from a
state capital are less likely to remain open. For instance, a school that is a 3-hour drive
from the state capital is likely to offer around 2 days less schooling as compared to a
school that is an hour’s drive. Rural schools offer almost 8 days less schooling than urban
schools. There is also substantial provincial variation in the supply of schooling. The
coefficients on the provincial indicators (not reported in the table) show that some
provinces offer almost 10 school days less than the average, while other provinces offer
7–8 days more than the average. The overall picture appears to be that the supply of
schooling is more closely related to the rural or provincial location of a school than the
type of administration.21
Table 4
Supply of schoolinga
School administration and locationb n Mean (standard deviation)
1. Public 548 150.37 (11.08)
2. Public-urban 113 159.06 (6.988)
3. Public-rural 435 148.12 (10.83)
4. Private 24 163.54 (4.662)
5. Private-urban 21 164 (4.593)
6. Private-rural 3 160.33 (4.618)
Teacher resources in schoolc
7. Single-teacher school 83 144.85 (11.67)
8. Two-teacher school 142 148.10 (10.96)
9. Multiple-teacher school 347 153.54 (10.34)
a Supply of schooling is defined as the number of days that a school is open during the school year.b t Tests (at the 5% level) reject the null hypothesis that there is no difference in the mean number of days that
schools are open across school administration and location.c t Tests (at the 5% level) reject the null hypothesis that there is no difference in the mean number of days that
schools are open across schools with different teacher resources.
21 The province level averages mask substantial intraprovince differences in the supply of schooling. Within
the same state, the supply of schooling may vary from 110 to 172 days in a school year.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 143
While our examination of the data has provided some idea about the source of supply
differentials, it also raises questions. What are the factors underlying the regional variation
in the supply of schooling? Observations during the data gathering exercise suggest that
these variations may be related to differences in policy regarding teacher pay collection,
local holidays and teacher meetings. For example, in some rural areas, teachers are
allowed 3 days to collect their monthly pay from the district administrative office. Some
teachers use their weekends to collect their pay, while others collect their pay on
weekdays. The frequency of teacher training seminars/meetings also varies substantially.
Teachers in some districts attend one seminar/meeting a week, while in other districts,
there are very few seminars/meetings. Another explanation for regional differences in
supply lies in different levels of school supervision across districts. In several rural areas,
there is almost no supervision, and school closures may be unknown to district supervisors
(Marshall and White, 2000).
As is clear from the discussion, a complete study of school attendance requires an
analysis of the demand for and the supply of schooling. Despite the limited supply side
analysis, our ability to identify the relative influence of demand and supply factors in
determining school attendance is by itself an important step in incorporating supply side
issues into an analysis of school attendance.
4.2. Educational production functions
Least squares and selection-corrected estimates of the four educational production
functions for Grade 2 and Grade 4 are presented in Tables 5 and 6, respectively. The
selection-corrected results control for the potential bias that may arise from estimating
regressions over samples of students who attended school on the days that the tests were
administered.22 For Grade 2, the selection patterns for both Spanish and Mathematics are
positive and statistically significant, indicating that unobserved characteristics that have a
bearing on test scores are positively correlated with school attendance. For Grade 4, the
selection patterns are not as clear. A comparison of the two sets of results (OLS versus
selection corrected) shows that there are very few sign changes on the estimated
coefficients, and while the magnitude of the coefficients for Grade 2 are substantially
affected, for Grade 4, the changes are minimal. Since we detect some signs of selection
bias, the discussions in this section are based on the selection-corrected estimates.23
We now examine the effect of various sets of characteristics on test scores. The age of a
child does not appear to play an important role in determining test scores, although there
are clear gender differences. Girls score higher than boys do by about 1–1.7 points on
Spanish examinations, although in Mathematics, at least for Grade 4, it appears that boys
perform better. The favorite subject dummy variable is included in order to control for
23 It is well known that the selection procedure is quite sensitive to specification of the selection equation as
well as to departures from normality. We experimented with some minor changes in specification, but the limited
availability of identifying information precludes a through examination. A prudent approach may be to repose
greater confidence in those coefficients that are robust to changes in the estimation approach.
22 The selection-corrected estimates are maximum likelihood estimates based on Heckman’s (1979)
correction procedure. The probability of attending school on the day of the test was specified as a function of
individual, school and teacher variables. Detailed estimates are available on request.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153144
subject-specific unobservables such as hard work, motivation or interest. This variable is
positive and significant for Mathematics but negative (and significant) for Spanish, which
implies that lower-scoring students may be choosing Spanish as a sort of default option
since they may find it to be the easiest subject.
Across both grades, attending preschool does not appear to confer any significant
advantages, although it is possible that the inclusion of several other family character-
istics makes it difficult to isolate the effect of attending preschool.24 Parental attitudes
24 Although we recognize the possibility that attending preschool may be an endogenous decision, we do not
pursue this issue as it is not the focus of our work. An informal examination of the effect of this variable was
carried out by examining results that excluded this variable. As may be expected, there were no substantial
differences in our estimates.
Table 5
OLS and selection corrected estimates of the test score equations—2nd grade (t statistics)
Variable OLS Spanish Selection-corrected
Spanish
OLS Math Selection-corrected
Math
Intercept 4.061 (0.509) � 6.133 (� 0.653) 29.468 (4.491) 10.746 (1.393)
Child characteristics
Age 0.264 (1.719) 0.241 (1.817) 0.202 (1.015) 0.122 (0.664)
Female 1.032 (2.776) 1.659 (4.097) � 0.683 (� 1.634) � 0.157 (� 0.350)
Favorite subject
(Spanish/Math)
� 0.837 (� 1.915) � 0.895 (� 2.449) 1.606 (3.630) 1.462 (3.428)
Family characteristics
Child attended preschool 0.556 (1.259) 0.105 (0.286) 0.536 (1.067) 0.441 (0.963)
Parental help 1.134 (2.068) 0.868 (1.950) 1.897 (3.385) 1.814 (3.411)
Father’s education 0.471 (3.441) 0.392 (3.348) 0.426 (3.110) 0.388 (2.799)
Mother’s education 0.245 (1.981) 0.176 (1.605) 0.013 (0.097) � 0.036 (� 0.255)
Parents active in school 2.418 (1.773) 1.303 (1.279) 2.489 (1.953) 2.109 (1.798)
Wealth 0.987 (5.692) 0.783 (5.679) 1.498 (8.271) 1.388 (8.172)
Teacher characteristics
Education 1.028 (1.889) 1.338 (2.184) 0.016 (0.038) 0.982 (2.046)
Experience � 0.046 (� 0.886) 0.003 (0.056) � 0.021 (� 0.345) 0.052 (0.801)
Teaching seminars attended 0.371 (1.153) 1.017 (2.713) 0.522 (1.599) 0.986 (2.530)
Test score 2.116 (0.710) 2.443 (0.647) 5.271 (2.084) 2.972 (0.996)
Teacher self-confidence 1.371 (1.901) 1.063 (1.113) 0.501 (0.659) 0.393 (0.392)
Classroom characteristics
Multigrade 2.587 (2.631) 1.721 (1.344) 1.542 (1.497) 0.250 (0.202)
Textbook availability 1.797 (1.736) 2.077 (1.740) 0.080 (0.084) 1.161 (1.004)
Class size � 0.059 (� 1.531) � 0.101 (� 2.191) � 0.133 (� 3.678) � 0.158 (� 3.685)
Selection-corrected term – 17.969 (39.319) – 18.124 (23.507)
Number of observations 7210 10,054 6938 9985
R2 0.122 – 0.113 –
Log-likelihood value – � 35,128 � 35,201
Notes: Additional regressors include an indicator variable for observations with missing information on parental
education, control variable for the percentage of total course material covered by teacher, a set of indicator
variables for 17 Honduran provinces and indicators for large city, city and town. t Statistics are heteroscedasticity
consistent and are adjusted for the clustered design of the sample.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 145
towards a child’s education are measured by two variables: parental help and parental
activity in school. Parental help appears to boost performance by about 1–1.8 points in
Grade 2 (in both subjects) and in Grade 4 (Spanish), but the dissipation of this effect for
Mathematics in Grade 4 probably reflects limited parental ability. The point estimates for
parental activity in the school are generally positive but not significant. Finally, the
parental education and wealth variables serve as proxies for household access to
resources, attitudes towards education and genetic ability. Except for Grade 2 Mathe-
matics, the effect of these variables is positive and statistically significant across our
estimates.
The teacher characteristics include conventional measures such as teacher education
and experience. In addition, we also have information on the current stock of teacher
Table 6
OLS and selection-corrected estimates of the test score equations—4th grade (t statistics)
Variable OLS Spanish Selection-corrected
Spanish
OLS Math Selection-corrected
Math
Intercept 21.140 (2.646) 23.558 (2.892) 20.041 (2.854) 20.476 (2.855)
Child characteristics
Age 0.054 (0.328) 0.060 (0.370) 0.045 (0.339) 0.046 (0.351)
Female 1.487 (3.565) 1.383 (3.315) � 0.817 (� 2.459) � 0.837 (� 2.510)
Favorite subject
(Spanish/Math)
� 1.476 (� 2.889) � 1.483 (� 2.910) 1.164 (3.329) 1.164 (3.343)
Family characteristics
Child attended preschool � 0.647 (� 1.420) � 0.659 (� 1.457) � 0.149 (� 0.424) � 0.149 (� 0.428)
Parental help 1.189 (2.372) 1.187 (2.377) 0.089 (0.205) 0.089 (0.208)
Father’s education 0.419 (4.015) 0.419 (4.025) 0.354 (4.439) 0.353 (4.456)
Mother’s education 0.312 (2.716) 0.314 (2.748) 0.211 (2.552) 0.211 (2.568)
Parents active in school 1.777 (1.577) 1.746 (1.561) 0.324 (0.376) 0.320 (0.374)
Wealth 1.244 (7.420) 1.235 (7.421) 0.665 (4.226) 0.665 (4.241)
Teacher characteristics
Education 0.733 (1.085) 0.578 (0.842) 0.600 (1.042) 0.575 (0.981)
Experience � 0.134 (� 2.914) � 0.142 (� 2.998) � 0.041 (� 1.155) � 0.043 (� 1.198)
Teaching seminars attended 0.129 (0.593) 0.112 (0.513) � 0.019 (� 0.098) � 0.021 (� 0.108)
Test score 3.335 (0.551) 3.176 (0.537) 1.453 (0.565) 1.491 (0.579)
Teacher self-confidence � 0.184 (� 0.258) � 0.225 (� 0.313) 0.087 (0.151) 0.084 (0.145)
Classroom characteristics
Multigrade 0.892 (0.845) 1.198 (1.142) 0.367 (0.426) 0.406 (0.473)
Textbook availability 0.720 (0.932) 0.583 (0.742) � 1.291 (� 2.093) � 1.327 (� 2.146)
Class size � 0.050 (� 1.591) � 0.041 (� 1.259) � 0.044 (� 1.671) � 0.043 (� 1.632)
Selection-corrected term – � 2.618 (� 2.316) – � 0.398 (0.351)
Number of observations 5359 7220 5024 7078
R2 0.189 – 0.119 –
Log-likelihood value – � 25,541 � 22,917
Notes: Additional regressors include an indicator variable for observations with missing information on parental
education, control variable for the percentage of total course material covered by teacher, a set of indicator
variables for 17 Honduran provinces and indicators for large city, city and town. t Statistics are heteroscedasticity
consistent and are adjusted for the clustered design of the sample.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153146
knowledge as measured by test scores on Spanish and Math exams. The number of
teaching seminars attended controls for knowledge of teaching skills, while unobserved
teaching ability may be captured by a self-reported measure of teacher confidence. For
Grade 2, the education level of the instructor and the number of seminars attended exert a
positive effect on test scores. For Grade 4, none of the teacher characteristics appears to be
systematically related to performance.
Classroom characteristics indicate whether several grades are simultaneously being
taught in the same classroom, whether there are enough textbooks available and the
number of students in the class. Except for class size, which indicates that a reduction in
the number of students in a class by one standard deviation would increase mean test
scores by 3.6–4.3% for Grade 2, and around 1.4% for Grade 4, none of the other class
characteristics are associated with test performance.
Despite the size of the sample and the presence of several variables that are not
conventionally available, we are unable to identify clear-cut, policy-relevant variables that
influence educational achievement.25 There could be several data-related reasons for the
limited effects of the teacher and classroom characteristics on test performance. For
instance, there may be limited variation in these characteristics. A look at the means and
standard deviations of these variables suggests that while this may be true for some of the
variables (e.g., teacher education), there does appear to be substantial variation in the data.
Correlation among these variables also does not appear to be a serious problem.26 Another
possible explanation is that the most important school and teacher variables that determine
academic achievement are unobserved (such as teacher ability or school management) in
our data set.27
4.3. School attendance28
As depicted in Eq. (12), we specify school attendance as a function of opportunity costs
(P) and benefits in the form of expected human capital gains (H) and the quality of school
facilities (Q), which may influence attendance but may not have a direct bearing on
student achievement. The estimates of the school attendance equation for Grades 2 and 4
are presented in Tables 7 and 8, respectively. The independent variables in these estimates
comprise three sets of variables corresponding to each of the three elements that may have
a bearing on school attendance. In Tables 7 and 8, the child, family and the first two school
25 Our inability to identify a clear set of policy-relevant inputs that boost academic achievement is not very
unusual (see Hanushek, 1986).
27 Regressions that include child and family characteristics and indicator variables for each school increase
the explanatory power of the models from a range of 0.113–0.188 to a range of 0.24–0.29. This suggests that
while differences across schools do influence test scores, we are unable to detect the factors that are responsible
for these differences.
26 Correlation among these variables does not appear to be substantial, as the condition number for the
correlation matrix of the teacher and class variables is less than 5.
28 Although we recognize that a large part of the variation in school attendance is due to differences in the
supply of schooling, we would like to reiterate that our attention in this section is restricted to factors that motivate
the demand for schooling.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 147
characteristics (time taken to reach school and whether the school has a lunch program) are
associated with the opportunity costs of school attendance. The next three variables, the
presence of a telephone connection, electricity and a composite variable of all other school
facilities, comprise the Q vector. The final variable is our measure of the expected human
capital gains of attending school. We have two measures of H, one from the OLS estimates
and the other from the selection-corrected estimates of the educational production
functions. Estimates of the attendance equation with both of these measures are presented
in each table.
Identification is always an issue in such models. The dilemma is deciding which
variables belong solely in the educational production function and may legitimately be
excluded from the school attendance equation. We present two sets of estimates based on
different exclusion restrictions. The first two columns of Tables 7 and 8 present estimates
based on the assumption that teacher and classroom characteristics influence the attend-
ance decision only through their effect on test scores. However, this assumption, especially
Table 7
Estimates of school attendance equation—2nd grade (t statistics)
Variable 1 2 3 4
Intercept 114.17 (13.567) 131.50 (23.813) 91.307 (7.439) 121.62 (15.650)
Child characteristics
Age � 0.884 (� 4.803) � 0.731 (� 4.140) � 1.099 (� 5.717) � 0.824 (� 4.646)
Female � 0.073 (� 0.228) � 0.274 (� 0.758) � 0.225 (� 0.714) � 0.592 (� 1.501)
Family characteristics
Child attended preschool � 0.432 (� 0.729) � 0.152 (� 0.265) � 0.867 (� 1.383) � 0.192 (� 0.330)
Parental help 0.013 (0.021) 0.855 (1.552) � 1.059 (� 1.405) 0.315 (0.517)
Father’s education � 0.339 (� 2.367) � 0.106 (� 0.898) � 0.661 (� 3.469) � 0.258 (� 1.772)
Mother’s education � 0.047 (� 0.486) 0.020 (0.223) � 0.152 (� 1.462) � 0.000 (� 0.003)
Parents active in school � 2.342 (� 1.193) � 0.516 (� 0.279) � 4.396 (� 2.231) � 1.218 (� 0.682)
Wealth � 0.366 (� 0.976) 0.268 (0.922) � 1.310 (� 2.600) � 0.171 (� 0.475)
School characteristics
Time taken to get to school � 0.021 (� 1.388) � 0.021 (� 1.406) � 0.020 (� 1.347) � 0.020 (� 1.375)
Lunch program 2.644 (1.201) 2.685 (1.224) 2.833 (1.352) 2.831 (1.342)
Telephone connection 2.067 (1.130) 2.069 (1.160) 3.211 (1.703) 2.689 (1.455)
Electricity connection 2.952 (2.219) 2.644 (1.987) 2.814 (2.082) 2.803 (2.032)
Other services 0.481 (1.294) 0.445 (1.188) 0.332 (0.842) 0.416 (1.063)
Estimated test score
H—from OLS specifications 0.911 (3.358) – 1.636 (4.225) –
H—from selection-corrected
specifications
– 0.460 (2.002) – 0.843 (2.819)
Number of observations 6139 6139 6139 6139
R2 0.408 0.401 0.419 0.408
Notes: Additional regressors include an indicator variable for observations with missing parental education, a set
of indicator variables for 17 Honduran provinces and indicators for large city, city and town. t Statistics are
heteroscedasticity consistent and are adjusted for the clustered design of the sample. Estimates in columns 3 and 4
include a set of classroom characteristics.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153148
for the classroom characteristics (which may be easily observed), is probably too strong.
Acknowledging this possibility, the set of estimates in columns 3 and 4 includes classroom
characteristics in the attendance equation. This set of estimates is based on excluding only
the set of teacher characteristics.29
We now turn to a discussion of the estimates. For all specifications in both grades,
age reduces the number of days attended. While it seems clear that as children age and
opportunity costs of attendance increase, it becomes less likely that they will attend
school, the marginal impact of this variable does not appear to be very large. For
Table 8
Estimates of school attendance equation—4th grade (t statistics)
Variable 1 2 3 4
Intercept 119.25 (9.634) 118.28 (9.184) 101.58 (7.679) 100.98 (7.533)
Child characteristics
Age � 0.786 (� 4.817) � 0.796 (� 4.833) � 0.855 (� 5.390) � 0.862 (� 5.416)
Female 0.310 (0.796) 0.362 (0.944) 0.186 (0.484) 0.270 (0.711)
Family characteristics
Child attended preschool 0.836 (1.361) 0.853 (1.385) 1.022 (1.704) 1.037 (1.721)
Parental help � 0.033 (� 0.048) � 0.042 (� 0.062) � 0.369 (� 0.573) � 0.382 (� 0.588)
Father’s education � 0.359 (� 2.079) � 0.363 (� 2.071) � 0.524 (� 3.080) � 0.524 (� 3.065)
Mother’s education � 0.200 (� 1.459) � 0.205 (� 1.482) � 0.353 (� 2.585) � 0.356 (� 2.614)
Parents active in school 0.769 (0.504) 0.751 (0.493) 0.672 (0.458) 0.668 (0.454)
Wealth � 0.000 (� 0.002) � 0.001 (� 0.003) � 0.502 (� 1.189) � 0.495 (� 1.172)
School characteristics
Time taken to get to school � 0.019 (� 1.253) � 0.019 (� 1.229) � 0.016 (� 1.057) � 0.016 (� 1.059)
Lunch program � 0.998 (� 0.418) � 1.001 (� 0.420) � 0.739 (� 0.308) � 0.795 (� 0.331)
Telephone connection 5.155 (2.825) 5.132 (2.811) 4.690 (2.742) 4.699 (2.739)
Electricity connection 1.377 (0.976) 1.444 (1.018) 1.412 (1.011) 1.437 (1.027)
Other services 0.446 (1.170) 0.463 (1.214) 0.257 (0.693) 0.280 (0.753)
Estimated test score
H—from OLS specifications 0.883 (2.109) – 1.367 (3.298) –
H—from selection-corrected
specifications
– 0.895 (2.102) – 1.369 (3.286)
Number of observations 4501 4501 4501 4501
R2 0.431 0.431 0.444 0.443
Notes: Additional regressors include an indicator variable for observations with missing parental education, a set
of indicator variables for 17 Honduran provinces and indicators for large city, city and town. t statistics are
heteroscedasticity consistent and are adjusted for the clustered design of the sample. Estimates in columns 3 and 4
include a set of classroom characteristics.
29 Even this exclusion restriction may not be appropriate for all the teacher characteristics. It is possible that
the educational qualifications or experience of a teacher may have a direct bearing on school attendance.
However, some of the other teacher characteristics such as seminars attended, self-confidence and test scores—
which are difficult for parents to observe—may be legitimate exclusions from the attendance equation.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 149
instance, a 12-year-old child in Grade 2 may miss 3–6 more days of school as
compared to a 7-year-old colleague. This effect translates into a 2–4% reduction in
attendance.
None of the family characteristics appear to be significantly associated with attend-
ance. While this may seem surprising, it is likely that these variables are exerting their
influence on the attendance decision through their effect on expected test scores.30 As
expected, the time taken to get to school is negatively associated with school attendance
in both grades, although the effect of this variable is not statistically significant, which
suggests that most children do not spend a prohibitively long time travelling to school.
As the descriptive statistics show, the mean travel time is only around 15–16 min. The
presence of a school lunch program defrays the costs of attending school and is expected
to be positively associated with attendance, however, the estimates show no evidence of
a systematic link.
We hypothesized that parents are more likely to send their children to school if it has
better facilities. There is some evidence to support this hypothesis. In Grade 2, the
presence of electricity in the school is associated with around 3 more days of school
attendance. The effect of this set of variables is slightly higher in Grade 4, where the
availability of a telephone connection appears to encourage 5 more days of school
attendance. Of course, these results should not be interpreted literally but with a view
that school facilities that may not have a direct bearing on test scores may nevertheless
send out easily observed quality signals that may encourage parents to send their children
to school.
The novel empirical result in these estimates is the effect of expected achievement gains
on the school attendance decision. Consistent with our hypothesis, the expected achieve-
ment variable suggests that the benefits derived from attending school plays an important
role in shaping parental decisions. Across both grades and all specifications, the effect of
this variable is statistically significant. An increase in the average score by about five
points increases school attendance in Grade 2 by 3–8 days. A similar increase for Grade 4
results in increases in school attendance by about 5–7 days. These effects translate into an
attendance increases of between 2% and 5% and show that expected achievement gains
exert an important influence on the demand for schooling. This finding is similar to Willis
and Rosen (1979) who found that expected earnings influences the decision to attend
college.
Overall, the school attendance estimates show that opportunity costs and the
expected benefits of attending school play a role in determining school attendance.
A comparison of the relative magnitudes of the two effects suggests that the impact of
opportunity costs in determining attendance may not be as important as the expected
benefits of attending schools. Of the several variables associated with the cost of
attending school, only the age of the child appears to exert a negative and modest
influence on school attendance. On the other hand, the effect of expected benefits on
30 Specifications that do not include the predicted human capital variables display a strong link between
some of the family characteristics, especially family wealth and school attendance patterns.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153150
school attendance appears to be quite large. The estimates indicate that a one-point
increase in expected benefits would be able to counteract the negative effect of a 1-year
increase in age.
The results suggest that rather than trying to reduce opportunity costs, policies designed
to increase school attendance may achieve their objective by encouraging appropriate
investments in school inputs. These investments may take the form of school facilities that
have a direct bearing on school attendance or on school inputs that influence educational
achievement, which, in turn, will encourage greater attendance. While this link appears to
be straightforward, identifying the appropriate school inputs that improve student achieve-
ment is still a difficult task.
5. Conclusion
In recent years, the substantial investments in the education sector in Honduras have
resulted in a rapid expansion of the primary education system. Access to primary school is
nearly universal and almost all children enroll in primary school. Thus, the focal issue is,
conditional on enrollment, how often does a child attend school?
The frequency of school attendance is an important determinant of academic
achievement, which is subsequently linked to repetition and desertion. Noting this chain
of events, this paper used recently collected data from a nationally drawn sample of
schools to specify and estimate a model of school attendance. Attendance was treated as
a function of opportunity costs and the benefits associated with school attendance. The
results from the estimated models displayed that while opportunity costs played a role,
perhaps a more important factor in determining school attendance are the expected
human capital benefits. The effect of expected achievement gains is important from a
policy perspective, as it suggests that investments in school inputs may be used to
achieve the same objective as programs designed to reduce opportunity costs of school
attendance.31
While school attendance was treated primarily from a demand perspective, an important
aspect of the paper was a decomposition of the school days missed into demand and
supply components. This decomposition indicated that between 60% and 71% of the days
missed during the school year may be attributed to the limited supply of schooling. The
magnitude of the supply side effect clearly indicates that a better understanding of school
attendance patterns in Honduras requires a detailed analysis of the factors that motivate the
supply of schooling.
Although limited by data constraints, we were able to provide some information on
the factors that influence the supply of schooling. Our analysis displayed that school
location plays a more important role in determining the number of days that a school is
31 Before following this course of action, one requires an assessment of the exact school inputs towards
which expenditure should be directed, as well as a cost-effectiveness analysis of programs designed to reduced
opportunity costs versus programs geared towards enhancing school inputs.
A.S. Bedi, J.H. Marshall / Journal of Development Economics 69 (2002) 129–153 151
open as compared to whether a school is publicly or privately administered. The regional
variation in the supply of schooling suggested that provincial or district level differences
in the manner in which schooling is organized may largely be responsible for variations
in the supply of schooling. From a policy perspective, the results suggest that allowing
greater private participation in the schooling system may not be enough to enhance the
supply of schooling. In order to isolate and understand the underlying factors that may
be driving supply and to design appropriate policy responses requires more information
on the manner in which the educational system is supervised in each province, as well as
information on policies regarding pay collection, local holidays and teacher meetings.
Notwithstanding the limited supply side analysis, our paper shows that a more fruitful
approach towards raising school attendance may lie not in reducing opportunity costs or
enhancing school inputs but in policies that target the supply of schooling.
Acknowledgements
We thank an anonymous referee for useful suggestions and Graham Pyatt for a helpful
discussion.
Appendix A
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Table A1
Supply of schooling (t statistics)
Variable 1 2 3 [Mean (standard deviation)]
Intercept 159.49 (168.24) 162.29 (124.48) –
School type
Public 5.799 (2.67) 3.732 (1.87) 0.958 (0.200)
Single-teacher school � 4.427 (� 3.42) � 3.672 (� 3.07) 0.145 (0.352)
Two teachers in school � 1.992 (� 1.90) � 0.871 (� 0.90) 0.248 (0.432)
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Time taken to reach school from
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Rural � 8.731 (� 7.72) � 7.553 (� 7.15) 0.765 (0.423)
Province indicators No Yes –
Number of observations 572 569 572
R2 0.231 0.408
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