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Contents: Original Research

Receipt of Prescription Contraception by Commercially Insured Women With Chronic Medical Conditions

DeNoble, Anna E., MSc; Hall, Kelli S., PhD, MS; Xu, Xiao, PhD; Zochowski, Melissa K., BS, MBA; Piehl, Kenneth, BS; Dalton, Vanessa K., MD, MPH

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doi: 10.1097/AOG.0000000000000279
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Women with chronic medical conditions are more likely than women without chronic conditions to report that their pregnancy was unintended1; unintended pregnancy rates as high as 50–60% have been reported in this population.2–4 Unintended pregnancy has significant implications for women with many chronic conditions given their higher risk for pregnancy-related maternal and fetal complications, including congenital heart defects in diabetes mellitus,5 stillbirth in rheumatoid arthritis,6 and preeclampsia in women with asthma.7

Among women with chronic medical conditions, family planning services, including contraceptive counseling and provision, are crucial to preventing unintended pregnancy and to reducing pregnancy-related complications.8–13 Prior studies examining the relationship between chronic conditions and contraceptive use have yielded inconsistent results1,14–18 and have been limited by their use of cross-sectional, retrospective,14 and self-reported data.14,16,17 Some studies focusing on single diseases such as diabetes mellitus have reported lower rates of receipt of contraceptive counseling, prescriptions, or services among women with these conditions.18 It is unclear whether chronic disease management overall or for specific diseases (eg, concern over hormonal methods in women with hypertension) affects the provision of contraception. Additional research is needed to clarify receipt of contraceptive services among reproductive-aged women, especially for a broader range of chronic conditions.

The objective of this study was to examine differentials in receipt of contraception by chronic medical condition status. Specifically, we compared receipt of prescription contraception over a 3-year period between women with and without chronic medical conditions who were enrolled in a commercial health plan.


This study used administrative claims data from women enrolled in a commercial health plan. Our study sample was drawn from a larger study of women with at least 54 months of continuous enrollment in Blue Care Network of Michigan. Blue Care Network is a large commercial health insurance plan with 4,500 primary care providers, including Title X providers. Blue Care Network provides medical and pharmacy benefits to more than 640,000 members. The Blue Care Network insurance claims database contained information regarding member year of birth, zip code, visit-level data on medical diagnoses and procedures, and pharmacy- (ie, prescription) or health care provider-dispensed (ie, inserted) contraception. All study data were extracted from deidentified Blue Care Network administrative claims that were submitted to Blue Care Network by health care providers on a daily basis. The Medical Informatics Department at Blue Care Network builds tables for claims analysis based on the claims received. According to the Blue Care Network, there is an extensive and rigorous monthly process that checks for data integrity and accuracy before the data are used for analysis in addition to routine audits to confirm the accuracy of claims submitted by health care providers. This study was reviewed by the University of Michigan Medical School institutional review board and received exempt status because the data did not contain any identifiable patient information.

Data were available for claims occurring between January 1, 2004, and December 31, 2009. An index date in 2004, 2005, or 2006 was randomly assigned to mark the beginning of a 3-year observation period. International Classification of Diseases, 9th Revision, Clinical Modification, Healthcare Common Procedure Coding System, and Current Procedural Terminology codes associated with each billed visit were extracted from the database.

To examine women who were between 21 and 45 years of age throughout the 3-year observation period, women who were 21–42 years old at baseline were included in this analysis. Additional inclusion criteria were: 1) at least 54 months of continuous enrollment, where the first 6 months were used to identify baseline characteristics and a subsequent 36-month period was used for measuring the exposure and outcome variables; 2) benefit coverage of contraceptive services and prescriptions throughout the 54-month continuous enrollment period; and 3) at least two outpatient visits between 2004 and 2009. Although the Blue Care Network offers several health maintenance organization plans, including Medicaid, only women enrolled in commercial insurance plans were included in this study (no Medicaid beneficiaries met the 54-month continuous enrollment criteria). Women with a hysterectomy were excluded as were women with a code consistent with ineligibility for contraception (ie, sterilization). We also excluded women with evidence of a pregnancy during the observation period to ensure that all women were potentially eligible for contraception.

Our primary outcome was receipt (yes or no) of prescription contraception during the 3-year study period. We examined pharmacy claims for hormonal contraceptive methods (ie, oral contraceptives, medroxyprogesterone acetate injections, vaginal rings, and transdermal contraceptives). Outpatient visit claims were used to identify provision of long-acting reversible contraception (intrauterine devices [IUDs] and subdermal implants). Diagnostic or procedural codes were used to identify IUD and implant placement, surveillance, and removal. Our secondary outcome was the proportion of months with a supply of contraception over the 36-month study period among women who had ever received prescription contraception. For pills, patches, and rings, we added the number of months supplied based on pharmacy claims. Each Depo-Provera injection was converted to a 3-month supply. Months supplied for intrauterine contraception and implants were calculated based on the number of months between the date of placement and the date of removal. For those with only placement or removal codes, months of coverage were calculated as the study end date minus the device placement date or as the removal date minus the index date. Those with no IUD placement or removal date who had an International Classification of Diseases, 9th Revision, Clinical Modification code for IUD surveillance were assigned a full 12 months of contraception for the year in which surveillance occurred.

Our primary exposure variable was the presence or absence of one or more chronic medical conditions, for which we coded women yes or no as having any of the following chronic conditions (in order of prevalence within our study population): uncomplicated hypertension, asthma, hypothyroidism, diabetes, obesity, rheumatoid arthritis, inflammatory bowel disease, and systemic lupus erythematosus. We considered a range of chronic conditions that are relatively common among reproductive-aged women,19 require frequent interaction with health care providers, and provided a sufficient analytic sample size. Other conditions such as depression and sickle cell disease were initially included but ultimately excluded as a result of insufficient subsample sizes, unreliable diagnostic coding, or both. We classified individuals as having a chronic medical condition if they had one or more of the eligible conditions identified by at least two visits with diagnostic codes corresponding to that specific condition.20–22 Women were classified as having “no chronic condition” if they did not have any of the chronic diagnoses listed or if they had fewer than two visits with a disease code.

Cervical cancer screening was included as a covariate because we hypothesized that contraceptive services might occur at the time of other preventive reproductive health services such as cervical cancer screening. All outpatient visits were used to identify receipt of cervical cancer screening using relevant Current Procedural Terminology and Healthcare Common Procedure Coding System codes. This covariate was categorized into none, one episode, or two or more episodes over the 3-year observation period.

Other covariates included characteristics of health care visits and participants. Visits were classified as problem-focused or health maintenance based on Healthcare Common Procedure Coding System codes. Age was included as a categorical variable (21–29 years old or 30–42 years old, because recommendations for the frequency of cervical cancer screening differ by these age groups).23 Member zip codes were used to link to the 2006–2010 American Community Survey data from the Census Bureau to create a community-level indicator of socioeconomic status (median income at less than 200% or 200% or greater of the federal poverty level for 2006).24

We first examined bivariate associations between chronic condition status (overall and for specific diseases), covariates, and our primary outcome (ie, receipt of prescription contraception) using χ2 tests. A subanalysis of those who received any contraception was performed using the Wilcoxon rank-sum test to examine differences in the mean proportion of months of contraception over the 3-year study period between women with and without chronic conditions. Multivariable logistic regression was then used to examine the relationship between the presence of a chronic condition and receipt of prescription contraception within 3 years while controlling for other covariates. Covariates that were significantly related to the exposure, outcome, or the exposure and outcome in bivariate analyses (P<.05) were included in the multivariable regression analysis. Finally, differences in the proportion of months with a supply of contraception between women with and without chronic conditions were examined using multivariable linear regression.

To detect a 15% difference in receipt of contraception between women with and without a chronic medical condition,18 with an α of 0.05 and 80% power, we needed a sample of 382 women per group. All data analyses were performed using SAS 9.3. A two-sided P value <.05 was considered statistically significant.


The selection of our sample is presented in Figure 1. Of our final sample (n=11,649), 16.0% (n=1,862) met criteria for at least one chronic condition. The prevalence rates of chronic conditions were as follows: hypertension (5.5%), asthma (4.6%), hypothyroidism (3.7%), diabetes (3.3%), obesity (2.9%), rheumatoid arthritis (0.6%), inflammatory bowel disease (0.4%), and systemic lupus erythematosus (0.2%). Table 1 presents the baseline characteristics of women by chronic condition status. A higher proportion of women with chronic conditions experienced a health maintenance examination (58.3% compared with 30.1%; P<.001) compared with their counterparts. Women with chronic conditions also had more outpatient visits on average over the 3 years than women without a chronic condition (mean visits 16.0 compared with 4.9; P<.001). Similarly, higher proportions of women with chronic conditions had cervical cancer screening at least once in 3 years than their counterparts without a chronic condition (56.8% compared with 44.1% for women 21–29 years old and 57.2% compared with 44.2% for women 30–42 years old; P<.001 for both comparisons).

Fig. 1
Fig. 1:
Study design inclusion criteria: participants were required to have 1) at least 54 months of continuous enrollment; 2) benefit coverage of contraceptive services and prescriptions throughout the 54-month continuous enrollment period; and 3) at least two outpatient visits between 2004 and 2009.DeNoble. Contraception in Women With Chronic Conditions. Obstet Gynecol 2014.
Table 1
Table 1:
Demographic and Health Care Visit Characteristics of Eligible, Insured Women Aged 21–42 Years Enrolled in the Blue Care Network of Michigan, by Chronic Condition Status

Overall, 39.8% (n=4,641) of women ever received prescription contraception during their 3-year observation period. Among contraceptive users, hormonal methods (n=4,367 [94.1%]) were more common than long-acting reversible methods (n=274 [5.9%]).

Fewer women with chronic conditions (33.5%) than without a chronic condition (41.1%) ever received prescription contraception (P<.001) (Table 1). After adjusting for covariates, women with at least one chronic condition were less likely than those without a chronic condition to have received any prescription contraception (adjusted odds ratio [OR] 0.85, 95% confidence interval [CI] 0.76–0.96; Table 2).

Table 2
Table 2:
Bivariate and Multivariable Logistic Regression of Receipt of Prescription Contraception in 3-Year Study Period, by Chronic Medical Condition Status

Other covariates significantly associated with receipt of contraception in multivariable models included the number of outpatient visits over 3 years (adjusted OR 0.99, 95% CI 0.98–0.99), yearly cervical cancer screening (adjusted OR 1.11, 95% CI 1.02–1.21), and younger age group (adjusted OR 3.82, 95% CI 3.49–4.19) (Table 2).

Results were similar in nearly all subanalyses for specific chronic conditions. In unadjusted analyses, women with hypertension, hypothyroidism, diabetes, asthma, inflammatory bowel disease, and rheumatoid arthritis had lower rates of receiving contraception than women without those conditions (Table 3). In multivariable models, there were no longer any differences in receipt of contraception between women with each individual chronic condition and those with no chronic condition after adjusting for covariates (Table 3).

Table 3
Table 3:
Logistic Regression of Receipt of Prescription Contraception in 3-Year Study Period, by Chronic Medical Condition Status for Selected Conditions

Among those who received prescription contraception (n=4,641), the unadjusted mean proportion of months of contraceptive supply was lower in women with chronic conditions (0.51) than in women without chronic conditions (0.55; P=.025). After adjusting for covariates, however, the mean proportion of months of supply was similar between women with and without chronic conditions (β=−0.02, 95% CI −0.05–0.01, P=.255; data not shown).


We found that commercially insured women with chronic conditions received prescription contraception at a lower rate than their healthy counterparts, potentially placing them at risk for unintended pregnancy and pregnancy-related sequelae. Our findings, along with others,18 point to missed opportunities to reduce these risks among women with chronic conditions.

Women in our study had insurance coverage for contraception and were seen at least twice by a health care provider over 3 years. Although other preventive services, like cancer screening, might benefit from a higher frequency of health care encounters,25 we found that more frequent visits were associated with a lower odds of receiving contraception. Although understudied, time constraints, competing medical priorities, and a lack of health care provider knowledge appear to be barriers to contraceptive-related service delivery in women with chronic conditions.18,26 In addition, the considerable amount of time required for contraceptive counseling and the fact that contraceptive services are poorly integrated into preventive care may further compound the problem.26

We recognize that women with chronic conditions may have contraindications to some contraceptive methods, which we were unable to measure here. However, even women with chronic conditions should have at least one effective option (eg, nonhormonal copper-containing IUD)27,28 but may not be offered these methods by their health care providers. Previous studies demonstrate that health care providers overestimate the adverse health consequences of contraceptive methods in certain chronic conditions. For instance, Eisenberg et al29 and Toomey et al30 suggest that health care providers are uncomfortable prescribing contraceptives to patients they perceive to be at higher risk for adverse events such as those with diabetes and hypertension. This reluctance persists despite the availability of evidence-based guidelines on contraception eligibility among women with chronic conditions.27,28

Under the Affordable Care Act, insurance coverage of the full range of contraceptive methods and associated office visits is required without copayment. The ongoing debate surrounding contraceptive coverage provides an opportunity to clarify what aspects of our health system should be targeted to decrease unintended pregnancy, including contraceptive services for women with chronic conditions. For instance, our previous work demonstrated that lower out-of-pocket costs are associated with an increase in IUD use among commercially insured women.31 By requiring insurance coverage for long-acting contraceptive methods, women with chronic medical conditions may have improved access to safe, highly effective methods. Further research on the effect of the Affordable Care Act on women's health should include an assessment of its effects on the delivery of all preventive women's health services, including contraceptive services.

We recognize several limitations in our study. First, the use of claims data limited our ability to directly measure pregnancy intention and contraceptive behaviors. We could not measure whether women actually used their contraceptive pills. Second, we could not assess the use of out-of-plan services or uncovered methods such as nonformulary pills, condoms, or partner sterilization. Thus, we may have underestimated the prevalence of contraceptive use in this population. Additionally, our results may not be representative of all reproductive-aged women with chronic conditions. As would be expected as a result of our selection criteria, our study population is slightly older than women in the National Survey of Family Growth but similar otherwise. Rates of prescription contraception in our study seem slightly lower than expected based on National Survey of Family Growth data for privately insured, nonsterilized women.32 In part, this observation may be the result of differences in ascertainment (claims data versus self-report), use of out-of-plan services, or regional practice patterns, which make direct comparisons difficult. Moreover, there is a dearth of information on population-based contraceptive prevalence rates among women with chronic conditions. Finally, an adequate analysis of specific chronic conditions was precluded by small sample sizes and inadequate power.

Despite these limitations, findings from our study provide additional evidence that women with a range of chronic conditions are at increased risk for unintended pregnancy compared with their healthy counterparts. Multifaceted interventions targeting health care provider training, care coordination, and individual behavior are likely required to improve contraception use among women with chronic conditions. Women with chronic conditions often receive their care from primary care providers, who may lack sufficient knowledge and training to offer the full range of contraceptive options.33,34 These encounters represent missed opportunities. Enhancing contraception education in residency training programs is clearly needed. Possible approaches include enhanced contraception education in primary care training, adoption of clinical decision support aids to increase the efficiency and accuracy of contraceptive counseling, and engaging health plans or systems to include family planning in ongoing efforts to improve coordination between health care providers, including adopting relevant quality measures.


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