Abstract
Research has insufficiently addressed the role of financial inclusion in migration decisions. Financial inclusion empowers people and provides the means to improve their own lives. We explore this relationship using data from the 2014 and 2017 waves of the Gallup World Poll Survey, which includes the first global measure of individual-level financial inclusion. Using a series of binary-choice models with sample selection, we find that financial inclusion meaningfully affects both intentions to migrate and preparations to do so. The likelihood of migration intentions and preparations increase with having an account, access to a debit card and the ability to make internet payments and to send and receive remittances. Saving for educational purposes, the ability to take out a loan, and savings via a savings club are also critical factors in converting migration intentions to preparations. Results show heterogeneous effects across rural and urban locations. Our findings imply that financial inclusion increases respondents’ ability to finance and save for migration costs and may increase their ability to utilize social networks for migration purposes. This has potentially important policy implications for policymakers seeking to achieve the Sustainable Development Goals, specifically targets 1.4, 8.10, and 10.7.
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Notes
We do not use 2011 data since the 2014 and 2017 waves asked far more detailed questions about the characteristics of respondents’ financial access.
GWP also includes territories such as Northern Cyprus and Palestine, but for the sake of this paper we refer to them as countries.
In some of the largest countries more interviews take place. For example, in 2014 researchers interviewed 3,000 and 5000 individuals in India and China, respectively.
Appendix A presents a list with all countries in our data set.
Household income is initially reported in the individual’s local currency (Gallup 2016). Local currency is then converted to international dollars using the World Bank’s PPP (2011) private consumption conversion factor to make household income comparable across countries. Respondents who have difficulty answering the income question are presented a set of ranges in local currency and are asked which group they fall into (Gallup 2016). This measure also relies on multiple imputation methodology to replace missing values.
The country-fixed effects specification (including a dummy variable for each country) allows us to control for the cross-sectional variation related to unobserved heterogeneity associated with individuals in each country. However, fixed effects probit models may produce biased estimates and standard errors due to the incidental parameter problem (i.e., in nonlinear models, as the number of groups increases towards infinity, the number of estimated parameters increases at the same rate, which may produce inconsistent estimates). However, consistent estimates depend on a sufficiently large number of observations per origin country (Ruyssen & Salomone, 2018). While no consensus exists as to a definitive number of observations that reliably overcomes the incidental parameter problem, the heuristic is generally 50 observations per group. In our sample, there are an average of 1,900 migration intentions and 25 migration preparations per origin country.
The index is the mean of valid items multiplied by 100 and is only calculated if respondents had more than 7 out of 10 valid scores. For more information on the construction of the EB index see Gallup (2016).
Sample weights provided by Gallup are used to estimate all descriptive statistics but are not used in the regression analyses. In the regressions we do not include the weights because the weights are constructed using our control variables. Gallup uses population statistics to weight the data by gender, age, and when possible, education or socioeconomic status (Gallup, 2016). When using these control variables in a regression, the survey weights become redundant and worse, may add statistical imprecision (Solon et al. 2015).
We tested the estimated coefficients and found evidence that the covariates varied significantly by rurality, justifying the location-separated analysis.
Further discussion on the descriptive statistics can be found in Appendix D.
Results are available upon request from the authors. Our results are robust to using only the first principal component or equally weighting the six principal components in the index.
The effect of having an account could be related to sending and receiving remittances, which may reduce the importance of the effect of having an account on migration decisions. We find a small, significant correlation between having an account and sending (ρ = 0.239) and receiving (ρ = 0.132) remittances.
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Acknowledgements
We would like to thank two anonymous referees for helpful comments and suggestions. We are grateful to Gallup, Inc. and The World Bank, for access to the Gallup World Poll and Financial inclusion data. We also wish to thank Chris Barrett for comments and suggestions. The findings and conclusions in this publication are those of the authors and should not be construed to represent any official NOAA or U.S. Government determination or policy.
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Smith, M.D., Wesselbaum, D. Financial inclusion and international migration in low- and middle-income countries. Empir Econ 65, 341–370 (2023). https://doi.org/10.1007/s00181-022-02331-4
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DOI: https://doi.org/10.1007/s00181-022-02331-4