Abstract
I estimate the effects of screening “low-risk” women for gestational diabetes using a regression discontinuity design and exploiting exogenous variation in testing at the overweight threshold of the body mass index in Finland. I find that screening low-risk mothers just above the overweight threshold increases the number of mothers diagnosed with gestational diabetes. There is a 1.5 percentage point, or 27%, increase in the probability of being diagnosed with gestational diabetes at the threshold, which translates into a 10.7 percentage point local average treatment effect given the 14.0 percentage point jump in the screening rates. The estimates on the effect on insulin treatment are, however, small and imprecise, suggesting that screening low-risk mothers did not result in diagnoses needing insulin treatment. The cost estimates in the existing literature suggest that the policy is cost-effective. The results also suggest that universal screening could decrease health disparities between mothers with low and high levels of education, given that gestational diabetes is treated if diagnosed. The effect on the probability of having an abnormal test result is over twice as great for the less educated mothers compared to the more educated mothers. Large effects of around 10–20% on adverse birth outcomes (low birth weight, macrosomia, metabolic testing, and C-section) can be ruled out.
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Data Availability
The dataset generated during the current study is not publicly available as it contains proprietary information that the authors acquired through a license. Information on how to obtain it and reproduce the analysis is available from the corresponding author upon request.
Code Availability
The do-file used for analysis is collected in the electronic supplementary material of this article.
Notes
Gestational diabetes used from here on. The American Diabetes Association defines gestational diabetes as follows: “any degree of glucose intolerance with onset or first recognized during pregnancy. The definition applies regardless of whether insulin or only diet modification is used for treatment or whether the condition persists after pregnancy. It does not exclude the possibility that unrecognized glucose intolerance may have antedated or begun concomitantly with the pregnancy.”
In Finland, the main rule is that all pregnant women should be screened for gestational diabetes with the oral glucose tolerance test; the few exceptions to this rule are presented in this paper.
That is, low-risk for developing gestational diabetes.
The Current Care Guidelines (Käypä hoito) are national, independent, evidence-based clinical practice guidelines that cover important issues related to Finnish health, medical treatment and prevention of disease. The guidelines are intended as a basis for treatment decisions and can be used by physicians, health care professionals and citizens. They were developed by the Finnish Medical Society Duodecim in association with various medical specialist societies.
When blood glucose levels in the body are too high (> 10 mmol/L), excess glucose can end up in the urine which can indicate gestational diabetes. Urine screening is conducted on all visits, even if the mother has tested negative for gestational diabetes with the OGTT.
In the analysis, I look at all instances of the OGTT regardless of the gestational week it was conducted. The data lack information on the week in which the test was conducted.
The cost of the test is from Terveystalo’s, a Finnish private health clinic, laboratory price list in 2015, the last year of the study period.
A descriptive population-based register study was conducted in Finland comparing women giving birth before the new guidelines were introduced in 2006 to women giving birth in 2010 after the new guidelines were implemented (Koivunen et al. 2015). The results suggest that the change in guidelines from a risk factor-driven approach to a comprehensive policy led to a significant increase—from 9.1% to 11.3%—in the prevalence of gestational diabetes, which was due to the increased number of mothers who could be treated with diet. Both the proportion and total number of insulin-treated women decreased significantly from 21.8% to 13.3%, suggesting that wider screening did not perform better in diagnosing women needing insulin treatment.
BMI or Quetelet index is a measure of relative size based on the mass and height of an individual; it is body mass divided by the square of height and always reported in \(kg/m^{2}\). A BMI from 18.5 to 25 may indicate optimal weight, while a BMI under 18.5 is considered underweight, and a BMI of over 25 is considered overweight. A person with a BMI of 30 or greater is considered obese.
The BMI is usually checked from a chart, where the y-axis represents the height of the person and the x-axis the weight. For example, a person who weighs 62 kg and is 158 cm tall would have a BMI of 25 according to the chart, while her actual BMI is 24.8 (62/(1.58*1.58) according to the formula. Hence, according to the chart, she is overweight, but according to the BMI formula, she is not. Similarly, if she weighed 61.5 kg, her weight would be rounded to 62, and hence, her BMI would be 25 according to the chart and 24.6 according to the formula.
16.7% (10.7 + 6) prevalence of positive test results for those who were screened due to crossing the overweight threshold versus 19% for those who were screened just under the threshold and are at risk.
The one-hour oral glucose challenge test (GCT) is a screening test for gestational diabetes that measures serum glucose concentration one hour after a 50 g oral glucose drink.
Estimated sample sizes for a two-sample proportions test (Pearson’s chi-squared test.)
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Acknowledgements
I thank Kristiina Huttunen, Manuel Bagues, Marko Terviö, Kaisa Kotakorpi, Matti Sarvimäki, Markku Siikanen, Katrine Løken and Libertad Gonzalez for valuable suggestions and comments. The paper has also benefited from comments of seminar participants at Helsinki Center of Economic Research (HECER) and the 11th Nordic Summer Institute in Labour Economics. I extend my gratitude to the journal editor, Professor van Soest, and the anonymous reviewers for their constructive and helpful comments. I thank the OP Group Research Foundation (Grant nos. 201600040, 201500016 & 201300023) and the Yrjö Jahnsson Foundation for funding.
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This study was funded by the OP Group Research Foundation and the Yrjö Jahnsson Foundation.
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Appendices
Appendix A Additional tables and figures
Appendix B Effect of screening on birth outcomes
The results suggest that the expansion of screening increased the number of cases that could be treated with dietary advice. A natural question is whether screening affects birth outcomes. However, it is not clear how screening might affect birth outcomes and the mechanism behind any such effects. Mothers are already given dietary advice at the beginning of their pregnancy, as Fig. 1 shows, and I could not find an effect on insulin treatment. Furthermore, there might be some unanticipated consequences if a mother has normal test results while having a “bad lifestyle” or diet or in the case of abnormal test results causing stress, both of which might cancel out the positive effects of treatment. It has been shown that maternal psychological factors like stress may significantly contribute to pregnancy complications and unfavorable development of the (unborn) child (see, e.g., Mulder et al. 2002, for a review).
A larger problem concerns issues of power. As I do not expect to see large effects of screening on many birth outcomes, and as adverse birth outcomes are rather rare in today’s Finland, the sample sizes needed to detect the effects would be enormous. Table 9 shows the population sizes needed to detect different effect sizes for multiple birth outcomes with the power of 0.8. The estimated sample sizes are calculated using Pearson’s chi-squared test and are estimations for a two-sample proportions test. In order to detect a 1% effect on low birth weight, I would need 10 million observations. With the current sample size of roughly 70,000 births varying with the bandwidth used, I am able to detect with high certainty an effect size of 7% to 20% depending on the outcome variable. Hence, it is highly unlikely that significant estimates would be found, given the small sample and expected effect sizes.
Table 10 provides estimates from the local linear regressions using a triangular kernel for birth outcomes. The estimates from the first-stage regression (i.e., the jump in the treatment) varies from 12.1 to 13.3 percentage points, depending on the bandwidth used. The optimal bandwidths obtained with the CCT bandwidth selector are now considerably lower (1.40 to 1.97 BMI units) than in the previous analysis. The intention-to-treat effects for adverse birth outcomes are small, ranging from −0.002 to 0.007 and imprecise due to the low fraction of adverse birth outcomes and insufficient mass around the cutoff. The IV estimates range from −0.012 to 0.054. Hence, I cannot rule out that there is no effect or a larger effect. For most of the outcomes, however, I can rule out effects larger than 10–20%. However, for C-section, which is the most frequent outcome, I am able to detect an effect of 7% with a power of 0.8 and a sample size of roughly 55,000, or 27,500 on both sides,Footnote 13 as shown in Table 9. Hence, the chances that the effect is larger than 7% are very small because the sample size is around 52,000.
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Riukula, K. The effects of screening for gestational diabetes. Empir Econ 65, 1931–1964 (2023). https://doi.org/10.1007/s00181-023-02397-8
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DOI: https://doi.org/10.1007/s00181-023-02397-8