Free school choice has often been argued to be a tide that lifts school quality through increased competition. This paper analyzes the underlying assumption that school quality is an important choice criterion for parents. Using a large and representative data set of over 15,000 Dutch primary school starters, we estimate models of school demand that incorporate heterogeneity in school preferences. Our results show that traditional measures for school quality matter, but other characteristics, such as school denomination and educational philosophy, are more important predictors of choice. Preferences for these school characteristics are strongly heterogeneous across parents.
Policies that aim to raise school quality, like the no child left behind act in the United States, focus on increasing the freedom of school choice. The idea behind these policies is that schools will have to provide higher quality education if they have to compete for students with other schools.
One key underlying assumption for school competition to raise the quality of education is that the quality of a school is an important choice criterion for parents. Parental preferences, however, are unlikely to be one-dimensional. Parents may also value other characteristics of schools such as the teaching philosophy, religious affiliation or geographical proximity. If parents have weak preferences for school quality relative to other school characteristics, quality competition between schools is likely to remain low, even when parents are given more opportunities to choose. In this case, free choice may stimulate schools to specialize by offering specific features instead of improving the quality of their program. Estimates of parental preferences for primary school quality (measured by test scores) are scarce, and the relative importance of other school characteristics has mostly been neglected.
This article provides an elaborate picture of parental primary school preferences by investigating heterogeneous preferences for school quality and a variety of additional school characteristics such as school denomination and teaching philosophy. The measures for school quality that we use are the assessment outcome of the Dutch Inspectorate of Education and school average test scores (CITO scores). Our study complements previous research by investigating to which extent school quality and these additional characteristics form preferences for schools and by studying how these preferences vary across parents.
We use a combination of administrative and survey data on over 15,000 Dutch parents of primary school students to estimate conditional and mixed logit models of school choice. The latter model allows estimates to vary across the population of choosers which is central to the identification of heterogeneity in preferences for school characteristics.
The Dutch context is of particular interest since, in contrast to other countries that have introduced free school choice more recently, it provides a case where school choice has traditionally been unrestricted. The observed patterns in school choice can be assumed to represent a general equilibrium and behavior will not be driven by recent policy changes or other interventions.
Our results firstly show that school quality matters: parents prefer schools with higher average student test scores and schools with a positive quality assessment of the Dutch Inspectorate of Education. We find heterogeneity in the response to the outcome of the Inspectorate’s assessment. Parents with higher education levels are more sensitive to the Inspectorate’s assessment than lower educated families. Similarly, schools with higher student achievements are on average more popular, but there is substantial variation in this preference among the group of lower educated people. About 32% of the lower educated families prefer schools with lower average achievement test scores over higher achieving schools. There are two potential explanations for these findings: (1) parents are unaware of quality differences at the school level or (2) they put a low weight on characteristics related to school quality when choosing a school.
Secondly, our results show that the schools’ denomination and the practice of an alternative teaching philosophy are important school characteristics that matter for choice. Parental preferences are also heterogeneous with regard to these other school characteristics such as whether a school is public, Catholic, Islamic, is dedicated to Montessori education or follows the educational philosophy of Rudolph Steiner. Even within specified socio-economic subgroups of the population, parents have varying preferences for particular school attributes. While some parents are willing to accept long daily travel distances to a school with a particular specialized profile, other parents avoid this school although it is in their immediate vicinity. Examples of these specialized schools are Islamic schools, which are very unpopular for the largest part of the population but very attractive to about 10% of the population. We further show that parents prefer schools that match their own religious beliefs. This effect is particularly strong for Islamic parents.
When looking at preferences for school instruction styles, we find that non-mainstream schools with an alternative teaching philosophy are on average less popular, but some higher educated parents strongly prefer these schools. Our estimates show that 26% of the higher educated parents prefer schools with alternative teaching concepts over mainstream education and are willing to accept a three to four times longer daily traveling distance to attend such a school.
Our findings with respect to the preferences for school quality are in line with previous research that has shown that parents with a lower socio-economic background put lower weights on observable school quality indicators. Hastings, Kane, and Staiger (2010) use data from Charlotte, North Carolina to show that black and lower income families have weaker preferences for primary and secondary schools with higher student achievements. The authors conclude that lower quality schools have weak incentives to improve because they attract parents that care less about quality. The authors further argue that high-quality schools perceive more competitive pressure, because the higher SES parents that choose these schools are more sensitive to differences in average student achievements.
Our findings are consistent with the recent work of Burgess et al. (2014) who show that parents in England value academic performance and proximity. Our results confirm their finding that socio-economically advantaged parents have stronger preferences for academic performance measured by test scores.
This article is also related to research that has focused on estimating parental preferences for secondary schools. Koning and van der Wiel (2013) investigate how parents in the Netherlands react to publicly available quality information about secondary schools. They show that newspaper published school rankings significantly predict future student enrolment: negative school quality scores decrease the number of enrolments and positive scores increase the number of students choosing that school. The largest effect was found in response to scores about the highest secondary school track (VWO). However, the size of the estimates suggests that even if parents are well informed, the effect of published quality indicators is generally small compared to the impact of other characteristics such as the overall reputation of a school track or the distance from home to school.
We show that quality indicators such as school average achievement test scores and the online published assessment outcome of the Inspectorate of Education matter for primary school choice. Besides school quality, the school’s denomination, teaching concept and proximity are important determinants for primary school choice. Preferences are strongly heterogeneous across parents.
The remainder of this article is structured as follows. Section 2 provides background information on the Dutch education system. Section 3 discusses the data. Section 4 describes our empirical strategy. Section 5 shows the estimation results. Section 6 concludes.
The Netherlands have a longstanding tradition in free school choice. Since 1917, parents can freely choose between state funded private and public schools. In contrast to other countries where free school choice policies are introduced more recently, the Netherlands provide a case to study school choice behavior that can be assumed to be closer to a “steady-state.” The results presented in this article can therefore be interpreted as evidence about how parental school choice preferences are shaped in a stable system without major policy discontinuities. This can be of particular interest for policy makers who are interested in the persistence of observed short run effects of free choice.
Dutch parents can in theory choose among all schools in the Netherlands. There are no school catchment areas or choice restricting school districts. School tuition fees are small or non-existent and therefore do not restrict school choice. The most obvious costs that parents face when choosing a more distant school are the opportunity costs of time. Both parents and their children will spend more time on traveling if they choose a more distant school since the school and the classmates of their children will be located farther away. Due to the high population density in the Netherlands, a number of schools is usually within walking or cycling distance.
Dutch parents can choose among schools with a variety of different religious affiliations and diverse educational concepts that fit their personal values best. Besides public schools (“openbare scholen”), there are schools with denominations like Catholic, Hindu, Islamic and Protestant schools. Schools which focus on a specific pedagogical concept are the “Brede school,” “Dalton school,” “Freinetonderwijs,” “Iederwijs,” “Jenaplan,” “Montessori” and “Vrije scholen.” The three most prevalent schools types that are usually within reach are Catholic, Protestant and public schools.
All school types are publicly funded, proportional to their student numbers. Schools that serve students from a more disadvantaged parental background receive some additional funding.
Oversubscriptions are sometimes a problem in larger cities in the western part of the country and are usually solved with admission lotteries. In some urban areas of the Netherlands, especially Amsterdam and Utrecht, student numbers are rapidly growing and parents with a higher socio-economics background seem to prefer schools with a high fraction of parents with a similar background. Therefore, a number of “white” schools in these areas are heavily oversubscribed. In the most southern province Limburg, where the data for this article were collected, there is little segregation. The area faced a decline in the number of children in recent years. Therefore, oversubscriptions and capacity constraints do not play a role for choice considerations.
Primary education in the Netherlands starts at the age of 4 and is compulsory from the age of 5. Parents in the region South Limburg apply directly at the schools where they would like to enroll their child. According to Dutch law, all schools (with a few exceptions) are obliged to accept all children that wish to enroll unless applications exceed capacity constraints. In the region that we analyze most children are accepted at the first school they apply. A large share of the schools in the Netherlands has a religious affiliation. For these schools, the same public finding rules apply as for public schools. In principle, these schools could refuse children that do not practice their religious principles, but schools are required to behave consistently in this respect. This means that once one child is accepted that does not meet these norms, the norm cannot be applied anymore. There are schools in other regions in the Netherlands that have access restrictions for these reasons, but in the region we analyze there are no schools that apply these specific norms.
Primary education in the Netherlands lasts for eight years, where the first two grades consist mostly of preparatory activities and can be compared to kindergarten in the United States. At the end of grade eight, a nationwide standardized central exam is taken – the so-called CITO test. This test is externally developed and objectively marked by the CITO institute, a non-profit organization, which is independent from the schools. So the test is not assessed by teachers of a particular school themselves. The conduction of the test takes place at the same time for all schools and lasts for several school days. The CITO test covers three main subjects: language, math and science. The outcome of the CITO test together with the teacher’s recommendation determines the secondary school track. There are three different types of secondary education tracks that vary in their degree of difficulty and educational focus. Only the highest track (VWO) permits access to studies at the University level. For the purpose of this paper, we use the school average performance of students in grade 8 to predict the choice outcomes of children that just entered in grade 1. Therefore, CITO scores are likely to contain latent lagged measures of school quality of the past eight years.
Figure 1 shows the distribution of the end of primary school student achievement tests and the recommended thresholds for secondary school tracking. The figure shows that the variation in the average achievement test scores across schools is substantial. If a school is to the right of the dotted vertical line, the average student at this school goes to the highest secondary school track. The average achievement test score of a school is generally not publicly known, but some schools publish their score on their websites for marketing reasons.
In order to maintain certain standards at the school level, the educational quality is monitored by the Dutch Inspectorate of Education which assesses schools through regular visitations and by evaluating student achievements. The Inspectorate’s assessment consists of class observations, and meetings with pupils, parents, teachers and the school management team. In addition, the Inspectorate investigates whether the school is able to perform a reliable self-evaluation and whether the school complies with statutory rules and regulations. One additional factor in the process of evaluation is the school’s average achievement test score (CITO score). There are three final outcomes of these quality assessments: “trusted,” “weak” or “unsatisfactory.” About 5% of the primary schools receive the label “weak” and less than 1% are “unsatisfactory.” The quality assessment of the Inspectorate is published online and parents can look up the rating of a specific school or compare the schools in the neighborhood. If schools continue to provide unsatisfactory quality or do not comply with the Inspectorate, they can be sanctioned by the Minister of Education. The most extreme measure is cutting off a school’s funding.
The school choice data analyzed in this article were collected by the Maastricht University research project Moelejaan in the southern part of the Dutch province Limburg. South Limburg is an urbanized area of 661 km2 and a population of about 620,000. It is surrounded by Belgium and Germany and only the north is connected to the rest of the Netherlands.
The data we use are a combination of administrative student data from schools and survey data from a questionnaire among the parents at these schools. 200 primary schools in this area participated in the study and provided student-level data. This is about 97% of the primary schools in the region South Limburg. The data consist of 16,852 children from three different cohorts that started school in 2007, 2008 and 2009. For the analysis, 1,065 children are dropped from the sample due to missing or non-existent home addresses; 13 schools are excluded because of missing end of primary school achievement test scores (CITO scores). The final sample consists of 15,000 students from 183 schools. For about 64% of these children, we have information about the education level of the parents from survey data, which we use in some parts of our analysis.
Table 1 shows descriptive statistics for five different school types. The table gives a first impression of how parents at various schools differ in terms of observables. Column (5) shows that schools with an alternative teaching concept attract particular students. Students at these schools travel a substantially longer distance from home to school and have on average higher educated parents. The performance of these schools is relatively weak in terms of student achievement and the schools are also more likely to be assessed as “weak” by the Inspectorate.
|Type of school||(1)||(2)||(3)||(4)||(5)||(6)|
|Percentage of parents lower educated||0.30||0.15||0.27||0.16||0.33||0.22||0.59||–||0.23||0.14||0.16||0.00|
|Percentage of parents middle educated||0.30||0.09||0.37||0.11||0.32||0.16||0.20||–||0.35||0.13||0.35||0.11|
|Percentage of parents higher educated||0.40||0.16||0.37||0.16||0.34||0.17||0.22||–||0.41||0.21||0.37||0.16|
|Percentage with “weak” Inspectorate||0.10||0.30||0.08||0.28||0.11||0.33||0.00||–||0.14||0.36||0.09||0.29|
|Std. school average CITO||0.02||0.76||0.08||0.97||−0.12||1.05||2.93||–||−0.68||0.95||0.03||0.98|
|Student distance in kilometers||0.993||1.13||0.713||0.77||0.854||0.98||2.628||3.10||1.457||1.87||0.83||1.01|
|Distance rank of the school||3.438||4.56||2.094||3.21||3.475||4.64||11.16||11.02||5.781||7.07||2.66||4.15|
|Number of schools||31||145||9||1||14||200|
|Average number of students||264.2||193.7||56.6||102.0||71.9||189.5|
The table also shows the average distance rank of the students that attend a particular school type. The average distance rank of all schools is 2.66, which means that students on average have 1.66 school options that are closer to their home location, but which they do not choose to attend. For schools with an alternative teaching concept, the average student-school distance rank is 5.78. The table shows that more specialized schools attract students which live farther away (i.e. that have more other schools closer to their homes).
Table 2 shows that there are many schools in the direct vicinity of the students’ homes. Figure 2 shows the distribution of the Euclidian distance to the chosen school. The median distance to the chosen school is 0.525 km. 90% of the parents choose a school that is within a 1.785 km radius from home, and few parents choose schools located far away from their home.
|Distance radius from home||Number of schools|
|Number of observations||15,435|
In order to investigate how parents choose between different primary schools we apply two different discrete choice models: the conditional logit and the mixed logit model. In the following, we will briefly discuss the intuition and limitations of both estimation techniques.
We use both the conditional and mixed logit models to allow a direct comparison between the different methods. Our benchmark model in the analysis is the mixed logit model. This model is less restrictive than the conditional logit model regarding the independence of irrelevant alternatives (IIA) assumption and crucial to identify heterogeneity in preferences without using one specific variable that represents the dimension of heterogeneity. The downside of the mixed logit model is that its lack of a closed-form solution creates computational limitations. The mixed logit further requires making an appropriate assumption about the mixing distribution of the random variables. In the following, we discuss the functional form of both models in more detail.
The conditional choice model was developed by McFadden (1973) and first applied to the context of school choice by Glazerman (1998). Intuitively, the conditional logit model compares the characteristics of the chosen school with the characteristics of all schools which are not chosen, using student-fixed effects.
In this model, the parents of each child i face the decision to choose between j different schools. Every school is associated with a certain amount of individual-specific utility . The model assumes that utility Uij can be described as a linear function of a child-specific component, a school-specific component , a school-child–specific component and a non-systematic random component
The utility that the parents of child i obtain from choosing school alternative j can be written in a linear form as:
We do not directly observe the utility level , but use the observed outcomes of the choice process which are revealed to us in the data. If the parents of a child choose school J, it is revealed to us that , i.e. that the utility level of the chosen school must have been larger than the utility of any other school in the choice set. The observed outcome variable is binary and takes on the value 1 if the school is chosen and zero otherwise. Using the observed outcomes of school choice, we can estimate how differences in and , which vary over different school options, relate to the probability that one given school has the highest amount of utility of all schools in the choice set.
Wi, the individual-specific characteristics do not vary over different choice alternatives. When estimating the model, all individual characteristics are invariant and fully collinear with the included individual fixed effects. Therefore Wi do not affect the choice probability. The resulting conditional logit model analyzes within person differences in preferences for schools. At first glance this appears unattractive since one of the main research questions of this article is how preferences for certain school characteristics vary across different socio-economic subgroups. In the conditional logit framework, estimating heterogeneity with respect to individual characteristics can be elicited by (1) estimating the model for subsamples of the population separately or (2) including interaction terms between individual characteristics and school-specific attributes.
One practical problem with the conditional logit estimation is the assumption of independence of irrelevant alternative (IIA). The IIA property assumes that the probability of choosing a particular alternative does not depend on the characteristics of other alternatives. Mixed logit models do not rely on this assumption.
The mixed logit model allows estimating the mean preference for a school attribute and the standard deviation of the mean preference coefficient. This appears particularly attractive for our research question since it allows a more direct estimation of heterogeneous preferences for certain school characteristics. The main advantage relative to the conditional logit model is that we do not need to specify the dimension in which a preference is heterogeneous. Using the mean and standard deviation, we can directly infer which share of the population has particular preferences for a specific school characteristic.
The mixed logit is also a convenient solution for avoiding the IIA property of the conditional logit. The mixed logit or random parameter logit that we apply was developed by Train (2009) and allows for random taste variation, unrestricted substitution patterns and correlation in unobserved factors. The mixed logit model works very similarly to the conditional logit model, but does not only estimate one point estimator that represents the mean preference of the population. Instead, the model assumes that coefficients βi vary over the population and are drawn from a normal or lognormal distribution. The mixed logit model can be represented in the following way in a random utility framework:
For the identification of parental preferences for school characteristics, it is important to keep in mind that other school characteristics that correlate with our measures of school quality might be confounding factors. One obvious candidate for such a characteristic could be the fraction of peers with a similar socio-economic background at a given school. However, including the percentage of peers at a given school as an additional school characteristic introduces potentially severe endogeneity problems that prohibit a direct interpretation of peer preference estimates. One additional empirical challenge for the identification is that achievement tests are likely to reflect school quality but might also be based on a priori differences between children. For instance, children might sort into schools based on their socio-economic background.
We analyze the preference for distance in Section 5.1 and the preference for school quality in Section 5.2. Section 5.3 analyzes the heterogeneity of preferences with respect to these indicators and Section 5.4 investigates to what extent school popularity varies between socio-economic groups. Sections 5.5 and 5.6 respectively analyze the importance of school denomination and alternative educational concepts.
Table 3 shows the estimates we obtain from the conditional logit estimation. The displayed coefficients represent the raw coefficients. Coefficients significantly larger than zero represent a characteristic that is related to an increase in the probability of choice and coefficients significantly lower than zero mean that this school characteristic is unpopular or unattractive among the population of choosers. The table shows that increased distance to a school option is negatively related to the probability of choice. Parents appear to have a strong preference for choosing a school close to their home location.
|Conditional logit||Conditional logit||Conditional logit||Conditional logit|
|Distance to school (100 m)||−0.211***||−0.211***||−0.211***||−0.211***|
|“Weak” Inspectorate evaluation||−0.401**||−0.283*|
|Std. CITO score||0.144***||0.127***|
|Number of schools||183||183||183||183|
|Number of students||15,000||15,000||15,000||15,000|
Figure 3 shows how the probability of choosing a school relates to the distance of a school option and investigates whether this effect is linear. The graph is based on a conditional logit estimation that includes one dummy variable for every 100 m unit of distance between home and school. The omitted category is having a school option within 100 m from home. The vertical axis displays the size of the coefficients and their 95% confidence intervals. As the distance between the home address and the school increases, the likelihood of choice decreases in a slightly convex trend. The difference between 0 and 1 km reduces the probability of choice more than the difference between 3 and 4 km. The marginal costs of traveling distance decrease slightly with increased distance.
The regressions in Table 3 include two measures for school quality: the outcome of the assessment of the Inspectorate, which is published online and the three-year school average achievement test score (CITO score), which is not available to parents for all schools. A negative assessment by the Inspectorate of Education is negatively related to the choice probability. Higher average student achievement test scores relate positively to the choice probabilities. These findings support the hypothesis that parents value these two measures of school quality when choosing among the different schools. In relation to the strong effect of distance, the preference for school quality seems to be rather weak. According to the estimated model, a school with a “trusted” rather than “weak” assessment outcome increases the willingness to travel farther by 190 m. The inclusion of quality indicators does not attenuate the point estimates for distance. This shows that parents’ preferences for distance appear to be uncorrelated with academic quality (as measured by the CITO score or Inspectorate outcome).
The estimates that we obtain from estimating the mixed logit models in Table 4 show similar results. In Table 4 we report the mean of the logit estimator and the standard deviation of the respective random parameter. The model shows that there is significant variation in the distance parameter, which suggests that some subgroups of the population are more sensitive to an increase in traveling distance than others.
|Mixed logit||Mixed logit||Mixed logit||Mixed logit|
|Distance to school (100 m)||−0.308***||−0.309***||−0.312***||−0.313***|
|Std. CITO score||0.190***||0.169***|
|SD distance to school (100 m)||0.131***||0.132***||0.134***||0.134***|
|SD “weak” evaluation||0.038||0.033|
|SD std. CITO score||−0.013||0.030|
|Number of schools||183||183||183||183|
|Number of students||15,000||15,000||15,000||15,000|
In both types of models, the size of the “weak assessment” coefficient is smaller when the standardized achievement test score is included. This collinearity between the two quality indicators is due to the construction of the Inspectorate’s assessment, which is partly built on the achievement test score (CITO).
We also investigate whether the results may to some extent be driven by selective response to the survey. Table 9 shows which variables are correlated to survey response. Responders are on average more likely to live closer to the chosen school, less likely to attend a school with a “weak” inspectorate assessment and more likely be come from a school with a higher CITO score. Table 10 shows how our point estimates differ between the full and the questionnaire sample. The point estimates are somewhat larger in the questionnaire sample, but they do not differ in a qualitative sense. In order to look at how preferences differ between socio-economic subgroups, we are restricted to use the questionnaire since we do not have information about the parental education level for the rest of the sample.
We now turn to the question whether preferences for school quality are heterogeneous among parents with a different educational background. In order to investigate heterogeneity, we split the sample based on the highest obtained educational degree of the father of the child.Table 5 shows estimates obtained from the conditional logit estimation for the three different subgroups. The estimates indicate that preferences for school quality vary substantially across groups. Higher educated families have stronger preferences for school average achievement test scores (CITO) when compared to middle and lower educated families. These last two groups do not significantly differ in their “taste” for high student achievements.
The interpretation of these coefficients requires some caution. What appears to be a difference in preferences could also be a result of asymmetric information about school quality. The achievement test (CITO) scores may not be known to the public as only some schools publish them on their websites. Lower educated families may in general have less information about school quality or face larger information costs. Besides that, schools with lower average student achievements may be more likely to be located in neighborhoods with more people from a lower socio-economic background. Our findings therefore do not necessarily have a causal interpretation.
Table 5 further shows that a “weak” outcome of the Inspectorate’s assessment is negatively related to the probability to choose the school. This effect varies across the three subgroups. Preferences for avoiding “weak” schools increase with the education level of the father. Holding everything else constant, higher educated parents would be willing to accept a 375 m longer way to school if they thereby could avoid sending their child to a “weak” labeled school. For lower educated families the respective distance is only 127 m.
|Higher educated||Middle educated||Lower educated|
|Distance to school (100 m)||−0.216***||−0.226***||−0.212***|
|Std. CITO score||0.256***||0.086||0.084|
|“Weak” Inspectorate evaluation||−0.811***||−0.448**||−0.269|
|Number of schools||183||183||183|
|Number of students||3,687||3,365||2,399|
The preferences for school distance appear to be homogeneous across subgroups. In the estimates that represent the preferences for school proximity (distance to school), we observe only minor differences.
The results we obtain from the mixed logit models in Table 6 give similar results with respect to the heterogeneity of preferences for school quality across families with different education levels. The benefit of the mixed logit model is that it allows us to investigate whether preferences are homogeneous within the specified educational subgroups. Table 6 shows that there is substantial variation in the preference for “weak” schools among the group of lower educated. About 14% of the lower educated appear to prefer weak schools over non-weak schools.
|Higher educated||Middle educated||Lower educated|
|Distance to school (100 m)||−0.294***||−0.347***||−0.324***|
|Std. CITO score||0.287***||0.121***||0.144***|
|“Weak” Inspectorate evaluation||−1.037***||−0.517***||−0.316**|
|SD distance to school (100 m)||0.112***||0.149***||0.145***|
|SD “weak” evaluation||−0.015||0.018||−0.300***|
|SD std. CITO score||−0.723||0.091||0.130|
|Number of schools||183||183||183|
|Number of students||3,687||3,365||2,399|
This finding suggests that a substantial fraction of this subgroup either does not know about the online published Inspectorate’s assessment or that they do not care about what the Inspectorate considers to be poor educational quality. Yet another explanation could be that this subgroup puts more weight on other school characteristics that negatively correlate with the Inspectorate’s assessment. One obvious candidate for such a characteristic would be the fraction of peers with a similar socio-economic background at a given school. Including the percentage of peers at a given school as an additional school characteristic introduces potentially severe endogeneity problems and the interpretation of peer preference estimates is not straightforward.
Figure 4 displays the relationship between school popularity and school average student achievements in a different way. Controlling for distance to the school, we estimate a conditional logit model with a specific dummy variable for each school. The size of the estimated dummy coefficients can be interpreted as its relative popularity relative to other schools given their geographical characteristics. Figure 4 plots the coefficient size of these school dummies against the achievement test (CITO) score of the respective school. The vertical axis represents the size of the school dummies from a conditional logit model. The horizontal axis displays the school average CITO score of the respective school. The slope of the fitted values line is positive and significantly different from zero, which means that the school’s “attractiveness” relates positively to the average student achievements of the school. However, it is apparent from the graph that student achievements alone are rather weak or noisy predictors of school popularity.
In the following, we investigate whether different subgroups of the population consider a given school similarly attractive. We estimate a conditional logit model that includes distance to school and one dummy for each school in our data set. We estimate this model for three educational subgroups separately. These groups are constructed based on the highest obtained degree of the father. The estimation output of this model produces 181 school fixed effects for each of the three educational subgroups. Each of these fixed effects yields a point estimate that represents the relative attractiveness in terms of revealed parental preferences.
The attractiveness of a given school in one socio-economic subgroup can now be compared to the revealed preference for this school in a different subgroup by looking at the correlation of the schools’ fixed effects between two different groups. Figure 5 shows the consistency of school popularity across educational subgroups. Figure 5(a) displays the size of the school “attractiveness” dummy for the higher educated on the vertical axis and the size of the same school dummy for middle educated on the horizontal axis. With fully homogeneous preferences for schools the slope of fitted values should be identical to a 45 degree line. The slope of the fitted value line is 0.93 and not statistically different from one. This correlation suggests that high and middle educated parents find the same schools attractive and have very similar revealed preferences. In contrast to that, the correlation in preferences of higher and lower educated families is much less consistent (Figure 5(b)). The correlation of revealed school attractiveness dummies is only 0.41 and statistically different from one. In Figure 5(c), where we compare the revealed preferences of middle and lower educated parents, the slope of the fitted value line is only 0.36, and statistically significantly different from one. This comparison between middle and lower educated parents shows that preferences for schools are remarkably different between these two groups.
We now investigate whether a school’s religious affiliation and educational concept matter for parental choice behavior. The mixed logit models in Table 7 show our most complete model of school choice. As in the previous regressions, we include distance and two indicators for school quality. In addition to that, we also include three dummies for Public, Protestant and Islamic schools. The omitted reference category is Catholic schools.
|All||Higher educated||Middle educated||Lower educated|
|Distance to school (100 m)||–0.337***||–0.325***||–0.375***||–0.336***|
|Std. CITO score||0.253***||0.411***||0.154***||0.146***|
|“Weak” Inspectorate evaluation||–0.458***||–1.057***||–0.389***||–0.311**|
|Alternative teaching philosophy||–0.262**||–1.056***||–0.260||–0.473|
|SD distance to school (100 m)||0.141***||0.130***||0.162***||0.149***|
|SD std. CITO score||–0.076||–0.010||0.029||–0.311|
|SD “Weak” Inspectorate evaluation||–0.238||–0.920*||0.130||0.072|
|SD Public school||–1.632***||1.872***||1.906***||–1.079|
|SD Protestant school||0.520||–1.023||1.194||–0.097|
|SD Islamic school||–13.236***||–5.438**||19.227*||–30.904***|
|SD alternative teaching philosophy||0.237||2.095***||0.073||0.426|
|Number of schools||183||183||183||183|
|Number of students||9,451||3,687||3,365||2,399|
Column (1) in Table 7 shows that public schools appear on average equally attractive as Catholic schools, but there is substantial variation in the preference parameter. About half of the population prefers one of the two types. Looking at the group of middle educated parents, we see that about 40% prefer Catholic over public schools. Protestant schools have on average a lower probability of being chosen than Catholic schools for higher and middle educated parents. About 15% of the higher educated parents prefer Protestant schools over Catholic schools. About 20% of the middle educated prefer Protestant schools over Catholic schools.
The one Islamic school in our data set is on average very unpopular for most parents, but this preference varies substantially over the population as revealed by the estimate of the standard deviation. About 10% of the parents have orthogonal preferences and find the Islamic school attractive.
Since the survey data we are using also contain a question on the religious affiliation of the parents, we can test whether preferences for the religious denomination of the school depend on the parents’ own denomination. In Table 8 we show how preferences for school denomination differ by the religion of parents. Column (1) shows that parents who indicated that they are not religious prefer public schools over Catholic and other religious schools. As expected, column (2) shows that Catholic parents prefer Catholic schools for their children. Column (3) shows that Islamic parents have particularly strong preferences for sending their children to an Islamic school. For this group, preferences are not only strong but also quite heterogeneous. The majority of Islamic parents seems to strongly prefer Islamic schools while others want to avoid these schools. Taken together the evidence presented in Table 8 shows that parents seem to prefer school that match their own religious beliefs.
|Distance to school (100 m)||–0.352***||–0.358***||–0.363***||–0.305***|
|Std. CITO score||0.363***||0.202***||0.190||0.301***|
|“Weak” Inspectorate evaluation||–0.782**||–0.584***||–0.174||–0.081|
|Alternative teaching philosophy||–0.467*||–0.409***||–0.514||–0.264|
|SD distance to school (100 m)||0.158***||0.149***||0.147***||0.133***|
|SD std. CITO score||0.219||0.040||–0.267||–0.339**|
|SD “Weak” Inspectorate evaluation||0.965||0.191||–0.033||–0.322|
|SD Public school||–1.964***||1.308***||–0.965||1.806***|
|SD Protestant school||–1.217||–0.019||0.262||0.158|
|SD Islamic school||0.097||0.048*||16.184***||–7.747***|
|SD alternative teaching philosophy||–1.122***||0.582||0.766||0.854|
|Number of schools||183||183||183||183|
|Number of students||1,510||6,028||295||1,618|
The regressions in Table 7 also include a dummy that specifies whether the school is devoted to an alternative teaching concept. Schools that belong to the “alternative teaching concept” category are Montessori, Jenaplan and Vrije schools. These schools usually grant their students a larger degree of individual freedom during the learning process and put more focus on fine arts, cultural and artistic education. The reference group in the regressions is schools with a mainstream educational concept. The mean preference shows that schools with an alternative teaching philosophy are generally less popular. However, there is substantial variation in the preference for these schools. About 26% of the higher educated parents prefer these schools over mainstream schools. Middle and lower educated families seem to largely avoid these schools.
An important point is that the inclusion of variables for different denomination types and an alternative teaching concept does not systematically alter the preference estimates for achievement test scores and the Inspectorate’s assessment. This supports that parental preferences for these special school characteristics are not captured by the available traditional measures of school quality.
Schools with higher average student attainments and better quality assessments have a higher probability of being chosen, but parental preferences for certain denomination types and an alternative teaching concept are heterogeneous and particularly strong in some subgroups of the population.
This article investigates which school characteristics matter for parental primary school choice in the well-established system of free school choice in the Netherlands. We find that school quality (measured by school average test scores) predicts school choice. Publicly available information on school assessments seems to influence choice behavior, particularly of higher educated families. However, this “taste for quality” is dominated by the strong preference for schools that are close to the homes of the parents. Our findings confirm evidence from the United States, which shows that lower educated parents appear to have weaker preferences for school quality.
Moreover, our findings show that parents have strong preferences for a school’s religious affiliation and the educational philosophy that is being applied at a school. Specific subgroups of the population have orthogonal preferences for a given school attribute. Parental choice preferences regarding these specialized schools with particular educational concepts have previously not been investigated.
Our results have implications for the discussion about the long run effects of free school choice that currently takes place in the United States, United Kingdom and many other countries. Some schools in the Netherlands seem to have specialized on particular socio-economic subgroups with specific norms and values. From a school perspective, specialization might be a rational response when being faced with more transparency about school quality and increased competition for students. Policies aiming to increase school competition may be the tide that lifts all boats, but they might also foster school specialization in the long run. The case of the Netherlands shows that specialized schools are able to offer something valuable to parents, that is different from traditionally measured academic quality.
We thank Ellen Greaves, Andries de Grip, Pierre Koning, Tyas Prevoo, Margriet van der Sluis, Benedikt Vogt, two anonymous referees, and conference participants at the ESPE (2013), IWAEE (2013) and ORD (2013) for valuable comments. We further thank Paul Jungbluth for generously sharing data and for providing valuable background information.
|Distance to school (100 m)||–0.003**|
|Std. CITO score||0.056***|
|“Weak” inspectorate evaluation||–0.133***|
|Alternative teaching philosophy||0.070|
|Number of schools||183|
|Conditional logit||Conditional logit||Mixed logit||Mixedlogit|
|Distance to school (100 m)||–0.211***||–0.218***||–0.313***||–0.315***|
|“Weak” inspectorate evaluation||–0.283*||–0.429**||–0.336***||–0.479***|
|Std. CITO score||0.127***||0.150***||0.169***||0.190***|
|Distance to school (100 m)||0.134***||0.130***|
|Std. SAT score||0.033||0.082|
|“Weak” inspection valuation||0.030||–0.012|
|Number of schools||183||183||183||183|
|Number of students||15,000||9,779||15,000||9,779|
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