Abstract
Chinese ethnic minorities are enjoying an era of resurgence, as their share of the population has risen by 50% from 1964 to 2010. Demographic forces alone cannot account for the rise. In this paper, we describe trends in ethnic minority identification and explore the determinants of identity with emphasis on the One-Child Policy, which raises the incentives to identify as a minority. Using nationally representative census data, we find that the policy significantly increases minority identity. The effects are especially large for persons in households with low socioeconomic status. This paper contributes to research on the history and demography of Chinese ethnic minorities, the impact of fertility policies, and the social construction of ethnoracial identity.
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Notes
For many reasons, measuring a person’s ethnic identity is challenging and problematic as Liebler et al. (2017) emphasize. Like most researchers, we only have responses from a survey (in our case, census). Thus, when we use the terms “changes in identity” and “changes in identification” in the paper, we are referring to changes in responses on the census. We are unable to examine whether such “response changes” are correlated with changes in other (broader) aspects of identity. However, we are confident that response changes are strongly correlated with changes in ethnic identity recorded in official government documents used for policy purposes.
Please see Appendix 2 which provides details regarding bounds on migration-driven effects.
Results are similar using father's education.
Our results are congruent with those reported by Wu and He (2018) who find that children of more educated, interethnic parents in Chinese autonomous provinces in 2005 are more likely to be identified as minorities as well as by Marteleto (2012) who finds that children of more educated, interracial parents in Brazil are more likely to classify their children as black.
In short, we take people alive in 1982, subtract those who died by 2000, and then add those born during 1983–2000. We assume that (1) people born in 1982 or earlier did not change their ethnic identity; (2) cohort- and sex-specific death rates between 1982 and 2000 were the same for Han and minorities (in fact, minority death rates were slightly higher); and (3) for Han and minorities, the estimated number of births since 1982 was proportional to the actual number of births since 1982 per female population aged 18–50 in 2000.
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Acknowledgements
We appreciate the insightful comments that we have received from the Editor, anonymous reviewers, and conference participants at the Population Association of America (PAA) annual meeting (2018) and the International Sociological Association (ISI) Joint Conference for Family and Population (2018) as well as seminar participants at the Lee Kuan Yew School of Public Policy (2018), Centre for Family and Population Research (2019), and the East Asia Institute (2019).
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Appendices
Appendix 1
See Table 9.
Appendix 2: Bounds on Potential Migration-Driven Effects
It is possible to calculate bounds on potential migration-driven effects with a simple mathematical exercise. We assume that there are two time periods, one before migration occurs (time 0) and another after migration occurs (time 1). We assume that there are two regions, one that sends minority migrants (the provinces that do not make policy exemptions for minorities) and another that receives minority migrants (the provinces that do make policy exemptions for minorities). We assume that ethnic identity is fixed across the population; the only change between periods is the migration that occurs from the sending region to the receiving region.
Based on hypothetical data on the initial number of Han (H) and minorities (M) in the two regions as well as the number of minority migrants (X), it is possible to run a regression model that mirrors the basic model in the paper when the effect of “time” is analogous to the effect of “fine.” In particular, the model is the following:
where y is minority identity; F is an indicator for time 1; E is an indicator for the receiving region; and \( \gamma \) are region fixed effects. To illustrate, consider some examples.
Example Suppose that the regions have an equal population size and an equal (initial) proportion of minorities:
H_sending | 50 |
M_sending | 50 |
H_receiving | 50 |
M_receiving | 50 |
X | 25 |
Then, \( \beta_{1} = - \;0.1667 \), while \( \beta_{2} = 0.2667 \). The ratio of the coefficients is 1.60.
Example Suppose that the receiving region has double the population size and an equal (initial) proportion of minorities:
H_sending | 50 |
M_sending | 50 |
H_receiving | 100 |
M_receiving | 100 |
X | 25 |
Then, \( \beta_{1} = - \;0.1667 \), while \( \beta_{2} = 0.2222 \). The ratio of the coefficients is 1.33.
Example Suppose that the receiving region has double the population size and a greater (initial) proportion of minorities:
H_sending | 50 |
M_sending | 50 |
H_receiving | 50 |
M_receiving | 150 |
X | 25 |
Then, \( \beta_{1} = - \;0.1667 \), while \( \beta_{2} = 0.1944 \). The ratio of the coefficients is 1.17.
General insights emerge from the analysis. Algebraically, the ratio of the coefficients is equal to the following:
where \( \theta \) is the initial fraction of Han, and P is the initial total population. One implication is that the impact of migration on receiving-provinces is limited by the extent to which the population size is larger in receiving-provinces than sending-provinces, i.e., the ratio decreases when the total population in the receiving region increases. Another implication is that the impact of migration on receiving-provinces is limited by the extent to which the proportion of minorities is higher in receiving-provinces than sending-provinces, i.e., the ratio decreases when the fraction of minorities in the receiving region increases.
Furthermore, it is useful to do an example which is more reflective of statistics about the regions. Relative to the sending region (provinces that do not make policy exemptions for minorities), the receiving region (provinces that make exemptions for minorities) had a population six times larger and a proportion of minorities four times larger.
H_sending | 98 |
M_sending | 2 |
H_receiving | 552 |
M_receiving | 48 |
X | 1 |
Then, \( \beta_{1} = - \;0.0099 \), while \( \beta_{2} = 0.0114 \). The ratio of the coefficients is 1.15.
Appendix 3
See Table 10.
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Francis-Tan, A., Mu, Z. Racial Revolution: Understanding the Resurgence of Ethnic Minority Identity in Modern China. Popul Res Policy Rev 38, 733–769 (2019). https://doi.org/10.1007/s11113-019-09543-0
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DOI: https://doi.org/10.1007/s11113-019-09543-0