Abstract
This paper investigates the gender wage gap for full-time formal sector employees, disaggregated by education level. The gap between the labor force participation rate of women with tertiary education and those with lower levels of education is substantial. There is no such gap for men. Hence, existing gender wage gap studies for Turkey, where we observe lopsided labor force participation rates by education levels, compare two very different populations. We disaggregate the whole sample by education level to create more homogenous sub-groups. For Turkey, without disaggregation, the gender wage gap was 13% in 2011, and women are significantly over-qualified relative to men on observed characteristics. Once we disaggregate the sample by education level, we show that the gender wage gap is 24% for less educated women and 9% for women with tertiary education in full-time formal employment. Observed characteristics only explain 1 % of this gap in absolute terms. We further disaggregate the data by public and private employment. The gender gap is higher in the private sector. However, women with tertiary education in the public sector are significantly better qualified compared to men, and consequently the adjusted gender wage gap is higher for women with tertiary education in the public sector. Our estimates also indicate a rise in the gender wage gap between 2004 and 2011.
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Notes
The Gender Development Index has 4 dimensions: differences in life expectancy at birth; differences in expected years of schooling (for the school age cohorts); differences in mean years of schooling for men and women aged over 25; differences in estimated Gross National Income (GNI) per capita for men and women. Differences in estimated GNI per capita for men and women is a composite measure of differences in labor force participation and the gender wage gap (UNDP 2015: Technical Note 4).
For the prime working age population (20–54 years old) 11% of women and 16% of men in Turkey have tertiary education degrees in 2011. Men with tertiary education make up roughly one quarter of male wage employees.
In other words, some women accept and defend patriarchal gender norms that regard men as breadwinner and women as homemaker.
Weichselbaumer and Winter-Ebmer’s meta-analysis covers studies mostly from developed countries, and around 75% of all studies are from the USA, Europe and other OECD countries. There is no case study from Turkey in the meta-analysis.
We present a more detailed discussion of Labor Force Survey methodology as well as descriptive statistics of independent variables in Appendix 3.
Dildar (2015) obtains data on patriarchal norms and religiosity from the 2008 Demographic and Health Survey for Turkey (TDHS, 2008). TDHS does not have data on wages.
If an interviewee declares that she is part-time employed, we classify her part-time employed. Also, if an interviewee reports that she is enrolled with any social security institution due to her primary job, we classify her as working in the formal sector. There are separate social security institutions for public sector employees, private sector employees, urban self-employed and farmers.
We do not have data on whether the sampled individuals are employed for a full year. Instead, we focus on formal sector employees who enjoy much more job security compared to informal sector employees.
In the tertiary sample, men work on average 46 (43) hours and women work 43 (41) hours in 2011 (2004) per week. In the less educated sample, men work on average 54 (52) hours and women work 50 (49) hours in 2011 (2004) per week.
We use Stata 11.1 Student Edition for all quantitative analysis both for descriptive statistics and for selection and decomposition analyses.
We calculate both the condition number and VIFs for every wage equation and in every case the calculated condition number and VIFs are lower than the respective thresholds. Variance Inflation Factor (VIF) is equal to 1/(1-R2) and VIF values larger than 10 are regarded as indicative of collinearity problems. Condition number is equal to the square root of the ratio of the Eigen value of the first independent variable entered into the model to the Eigen value of the last independent variable entered into the model. Calculated VIFs and condition numbers are available from authors upon request.
We do not discuss the individual contribution of each variable to selection or wage determination in each model due to space considerations. These estimates are available from authors upon request.
We calculate mean log differences between men and women as usual. In order to make our research results more accessible to non-economists, we convert the mean log differences between men and women to percentages as follows: If ln W – ln M = −0.222 ➔ ln (W/M) = −0.222 ➔ (W/M) = e-0.222 = 0.8. i.e. on average women earn 80% of men.
As we explain in previous paragraph, we do not prefer to include occupation categories and administrative tasks due to endogeneity in our main results. These results are available from authors upon request.
There is almost complete absence of state provision of or support for childcare. Additionally, childcare is generally regarded as responsibility of women. Hence women are at a disadvantage for jobs that require over-time or lengthy commutes.
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Acknowledgements
Earlier versions of this paper were presented in European Society for Population Economics Annual Conference in Braga (June, 2014); Bahçeşehir University Turkish Labor Market Research Network Conference in Istanbul (December, 2014); and International Association of for Feminist Economics Annual Conference in Berlin (July, 2015). We thank all conference participants; as well as anonymous reviewers and editors of Journal of Labor Research for their comments and suggestions. The authors declare that they have no conflict of interest.
Data used in this research is the proprietary material of Turkish Statistical Institute. Interested parties can obtain these data from TurkStatFootnote 16 at a reasonable price. A data appendix with additional results, and copies of the computer programs used to generate the results presented in the paper, are available from the corresponding author at htekguc@gmail.com.
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Appendices
Appendix 1: Female Population by Education and Employment
Appendix 2: Methodology
Derivation of Wage Estimation Model (Eq. 1)
We calculate the average wage gap as follows:
where E(YM) and E(Yw) are expected mean log hourly wages, E(XM) and E(Xw) are mean characteristics of male and female samples, respectively, and βM and βW are coefficients that determine the expected hourly wages. Threefold decomposition (Jann 2008) can determine the amount of mean outcome difference due to difference in observable characteristics, and the amount due to difference in coefficient estimates:
Endowment component refers to the difference between average observable characteristics related to the job market for men and women, such as age, tenure etc. Coefficients (for example, the amount that an extra year of tenure increase one’s wages) component measure the coefficients’ contribution to hourly wage differences. This component is the measure unexplained part. Finally, the interaction component accounts for the coexistence of simultaneous differences for endowments and coefficients between the two groups. The estimated decomposition takes on the following format:
If we re-arrange endowment and interaction terms, Eq. 3 can be reduced to Eq. 1 in the main text, which is the common presentation in the literature, and corresponds to Eq. 9 in Oaxaca and Ransom (1994), when the male wage structure is assumed to be the base wage structure. We present our empirical results in parallel to Eq. 1 because we note that in our empirical analysis, interaction effects are very close to zero in most of the cases and its combination with Endowment effect leads to no loss of significant information.
Appendix 3: Data
Labor Force Survey is the source of data for official statistics about employment. The survey aims to cover all households in Turkey (institutional population is excluded). Data is collected throughout the year (first week of every month) and the sample size is large enough to produce quarterly employment statistics both at national level as well as urban and rural areas of NUTS2 regions (there are 26 NUTS2 regions in Turkey). As a result, there are 52 strata (26 NUTS2 regions and rural and urban areas within each region). First, each Stratum is divided into clusters and the total number of clusters is 350. Than each cluster is further divided into blocks (containing approximately 100 houses in urban areas or whole villages in rural areas). Finally, each quarter 15 of households in each block is surveyed (TurkStat 2012a). The population of the NUTS2 regions differ widely hence weighting of estimates is necessary for representative results. The sampling weights are provided by TurkStat in the dataset. The response rate to the survey is 87% (TurkStat 2012b: XXII). We use the whole sample for the year in our study.
Appendix Table 8 (for 2011) and Table 9 (for 2004) present descriptive statistics for dependent and independent variables used in the regression analysis disaggregated by gender and education level. As can be seen from both tables single women are over-represented among working women compare to men. Moreover, women with zero children is also under-represented in the sample compare to similar men. These findings are probably due to the fact that women tend to leave labor force once they have children. And women with children who stays in the labor force are more likely to have more secure employment. As expected, women with tertiary education are over-represented in overall sample. Women in the formal, full-time employment are more likely to be younger, reside in urban areas, metropolitan cities (Istanbul, Ankara and Izmir) and western regions (first six regions). Finally, women are more likely to work in medium sized firms, in public sector and they have shorter tenure in in their current employers.
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Tekgüç, H., Eryar, D. & Cindoğlu, D. Women’s Tertiary Education Masks the Gender Wage Gap in Turkey. J Labor Res 38, 360–386 (2017). https://doi.org/10.1007/s12122-017-9243-x
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DOI: https://doi.org/10.1007/s12122-017-9243-x