Abstract
Recent studies have found that modern water supply systems played an important role in mitigating the mortality risks in major US cities in the early twentieth century. Modern water supply systems were installed also in Japanese cities during the interwar period. This study examines how the modern water supply system in Tokyo City reduced mortality risks in the interwar period. By employing a Bayesian disease mapping approach with a block-level lattice dataset of Tokyo for 1930, we found that wider access to purified water through water supply systems played an important role in mitigating mortality risks during the study period. Our estimation results show that clean water accounted for approximately 41.3 and 34.9 % of improvements in crude and child death rates, respectively, between 1921 and 1937 in Tokyo.
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Notes
Previous studies examining the economic history and demographics of Japan focused on the decline in infant mortality during the interwar period. These studies analyzed the impact of the countermeasures in rural areas on infant mortality (Saito 2008) and social work in a major city (Ogasawara and Kobayashi 2015).
See Ogasawara and Inoue (2015) for a more detailed discussion of this point.
Tokyo expanded its city area by incorporating five districts, 80 towns, and two villages on October 1, 1932, and thus, the original 15 wards in Tokyo are usually called old city (kyu shiiki). Throughout this paper, we focus only on this old city for the sake of consistency of statistics and discussions.
See Tables A.1 and A.2 in Online Appendix A for more details on the cause-specific mortality rates and proportion of cause-specific deaths to total deaths by year, respectively.
Figure A.1 in Online Appendix A, which shows the number of deaths per 1000 attributed to major infectious diseases, provides more clear disparities in trends.
Please see Online Appendix B.1 for the full description of the history of the water supply system in pre-war Tokyo.
Federation of Water Authorities (1931, pp. 105–106). The number of households in each city is obtained from Cabinet Bureau of Statistics (1933d, p. 210), Cabinet Bureau of Statistics (1933e, p. 367), Cabinet Bureau of Statistics (1933c, p. 256), Cabinet Bureau of Statistics (1933b, p. 312), and Cabinet Bureau of Statistics (1933a, p. 312).
For details on how these tests were performed, see Federation of Water Authorities (1931, pp. 12–45).
This criterion was implemented on the basis of evidence found by Robert Koch, also known as the founder of modern microbiology, that piped water that had been filtered to below this level would not cause cholera and typhoid (see Exner et al. 2003, p. 13). In fact, this standard remained in effect even after the war (see Ichikawa 1990).
In the “Regulations on the Use of Tokyo’s Water Supply,” the water pipes were laid by the city, but the pipes beyond the water meters were installed by certified companies with the permission of the city. This was to prevent tampering with the water meters and leakages caused by inferior materials. Therefore, it would have been difficult for households to tamper with their water use (see Bureau of Waterworks 1999b, p. 211).
For finer details of the historical documents used in our empirical analysis, see the Online Appendix C.
Note that child death rate is usually defined as the proportion of child deaths to the total population of children.
The data were obtained from a report based on the “Survey of Poor Requiring Support in Tokyo,” which was conducted in 1932 in preparation for the introduction of the Poor Relief Act. The survey identified the number of households eligible for relief under the Poor Relief Act (i.e., the number of households below the poverty line) to be 5961, comprising 26,257 individuals. For details on the poverty surveys conducted at the time, see Ogasawara and Kobayashi (2015) and Nakagawa (1985).
In fact, the modern medicine and medical technology in the early twentieth century were able to prevent the diseases, and thus, the demand for the medical treatments increased among the people in Japan (see Ikai 2010, p. 127).
The detailed estimation results for the PR model are presented in Online Appendix D.1.
By introducing spatial and heterogeneous random effects, the smoother posterior mean surfaces of the marginal effects are obtained for the SPR model rather than for the PR model. This improvement can be best seen in Figure A.2 in Online Appendix A, where the marginal effects for the PR model are presented.
See Fig. 2. Again, please note that we use the value of 1921 instead of 1920 because of the influenza pandemic between 1918–1920 in Tokyo.
Both the number of child deaths (0–4 years) and the population in Tokyo City are obtained from the ASCT (various years, vol. 19).
Please see Figure A.4 and Table 4 in Online Appendix A for the results.
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Acknowledgments
We are grateful to Alan Gelfand, Lionel Kesztenbaum, Ran Abramitzky, Yukitoshi Matsushita, and two anonymous referees for their valuable comments and encouragements. We would also like to thank the Tokyo Waterworks Historical Museum for their cooperation in gathering the historical documents for the present study. This study is partly supported by JSPS KAKENHI Grant Numbers 26885029 and 15K17036, as well as the Nakajima Foundation. The computational results are obtained using Ox version 6.21 (Doornik 2007).
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Appendix: Marginal effect of WATER and PHR
Appendix: Marginal effect of WATER and PHR
We can interpret the estimates in terms of the marginal effects of the covariates in the following way. Under the log link function, a 1 % increase in the coverage rate of the water supply and the poverty ratio, with the other factors fixed, changes the relative risk by \(\exp (\frac{1}{100}(\beta _1+\beta _3{\text{PHR}}_i)\) and \(\exp (\frac{1}{100}(\beta _2+\beta _3{\text{WATER}}_i)\), respectively, because the estimates are obtained based on the rescaled WATER and PHR. Similarly, an additional doctor and person over 60 years old change the relative risk by \(\exp (\frac{1}{100}\beta _4)\) and \(\exp (\beta _{5})\) times, respectively. A similar calculation applies in the case of the logit link function for the effect of the mortality rate on the odds ratio.
We also calculate the marginal effect of the countermeasures on the mortality rate per mil for each block. This effect under the log link specification is given by
Likewise, the marginal effects of PHR on the mortality rate are given by
The marginal effects of WATER and PHR on the mortality rate under the logit link specification are given by
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Ogasawara, K., Shirota, S. & Kobayashi, G. Public health improvements and mortality in interwar Tokyo: a Bayesian disease mapping approach. Cliometrica 12, 1–31 (2018). https://doi.org/10.1007/s11698-016-0148-3
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DOI: https://doi.org/10.1007/s11698-016-0148-3