Factors that did not contribute significantly to the fit of the model on likelihood ratio testing (P<.05) were excluded. Continuous variables were tested for departure from linearity by the addition of quadratic terms to the model, and potential interactions were tested by the addition of interaction terms and subsequent likelihood ratio testing on removal. A correlation matrix of the covariates was constructed to check for colinearity. Factors thought likely to be on the causal pathway between previous cesarean delivery and peripartum hysterectomy, such as placenta praevia, were not included in the multivariable model because this leads to overadjustment. To estimate the proportion of cases attributable to specific causes, we calculated population proportional attributable risks (etiologic fraction) by using the adjusted odds ratios from the multivariable analysis and the proportion of controls exposed as an estimate of population exposure.22 All analyses were carried out using STATA 9 software (StataCorp, College Station, TX). The funding sources played no part in the study design, data collection, analysis, and interpretation in the writing of the paper or the decision to submit the paper for publication.
All 229 eligible U.K. hospitals participated in the U.K. Obstetric Surveillance System, representing 100% participation. Sixty-one percent of hospitals returned all their monthly case notification cards, 87% of hospitals returned at least 11 of 13 monthly cards, and 91% of cards were returned overall. Only five hospitals returned seven or fewer cards; two were tertiary referral units and three local district hospitals. Data collection forms were received for 94% of notified cases (Fig. 1). There were 318 confirmed cases of peripartum hysterectomy in an estimated 775,186 women delivering,18–20 giving an incidence of 4.1 per 10,000 women delivering (95% CI 3.6–4.5). Information about 614 correctly selected controls was obtained. Compared with the controls, women who had a peripartum hysterectomy were, on average, older, more likely to be nonwhite, married, and nonsmokers, with a higher body mass index although with a similar socioeconomic profile (Table 1). They were also more likely to deliver preterm and have low birth weight infants.
Three hysterectomies were undertaken electively for management of malignancy (one ovarian, two cervical cancers), with the remaining 315 undertaken for management of hemorrhage (Fig. 1). Analysis of risk factors was carried out with only the 315 cases in which peripartum hysterectomy was undertaken for management of hemorrhage and their 608 correctly selected controls. The most commonly reported causes of hemorrhage were uterine atony (53%), morbidly adherent placenta (39%), uterine rupture (8%), and extension of uterine incision at delivery (6%). Other individual causes each accounted for 5% or fewer of cases.
After adjustment, the only sociodemographic factor significantly affecting the risk of peripartum hysterectomy was maternal age (Table 1), for which there was a linear increase in risk with increasing age. Women having a hysterectomy were six times more likely to be carrying twins. Hysterectomy was associated with both manual placental removal in a previous pregnancy (OR 12.5, 95% CI 1.17–133.0), previous myomectomy (OR 14.0, 95% CI 1.31–149.3), and previous uterine cavity instrumentation (OR 1.48, 95% CI 0.95–2.29), although the latter was not statistically significant.
Compared with controls, women who had had a peripartum hysterectomy were over three times (OR 3.52, 95% CI 2.35–5.26) more likely to have had a previous cesarean delivery. This risk increased with the number of previous cesarean deliveries, such that women with a peripartum hysterectomy were over eighteen times more likely to have had two or more previous cesarean deliveries. There was some evidence of an interaction between previous cesarean delivery and age; the risk associated with previous cesarean delivery was higher in women aged less than 35 years (OR 6.87, 95% CI 4.01–11.77) than in those aged 35 years or older (OR 2.21, 95% CI 1.22–4.01). After adjustment, an independent relationship between the risk of peripartum hysterectomy and parity was evident only for women of parity three and above.
Peripartum hysterectomy cases were more likely to receive augmentation in labor (OR 2.0) although less likely to have had labor induced (OR 0.68) (Table 1). They were also 14 times more likely to undergo cesarean delivery in the current pregnancy. To explore this relationship further and to eliminate the effect of previous cesarean delivery, we investigated the risk of peripartum hysterectomy associated with cesarean delivery in the current pregnancy in the subgroup of women who had not had a previous cesarean delivery, adjusted for age, multiple pregnancy, previous uterine surgery, manual placental removal, and myomectomy. From this we estimated the odds ratio of the effect of cesarean delivery in the current pregnancy, independently of these adjustment factors, as 7.13 (95% CI 3.71–13.7).
A number of factors in the current pregnancy thought to be on the causal pathway between previous cesarean delivery and peripartum hysterectomy were not included in the adjusted analysis, but were, by themselves, strongly associated with peripartum hysterectomy. Both uterine rupture and placenta accreta were strongly associated with peripartum hysterectomy risk. In the absence of controls with these conditions, we can only estimate the lower confidence limit of the odds ratio, which was 14.3 for uterine rupture and 99.5 for placenta accreta. Three (0.5%) of the controls and 38% of the cases had some grade of placenta praevia (89% major), giving an unadjusted odds ratio of 113.3 (95% CI 28.0–458.4). These represent very high risks but should be interpreted with caution, given the instability of the estimate. Nearly 70% of the cases who had had a previous cesarean delivery had abnormal placentation in their current pregnancy (Table 2), compared with only 30% of those who had not had a precious cesarean delivery (45 of 151 women, data not shown).
Estimated risks of needing a hysterectomy after delivery in different groups of women are shown in Table 3, calculated using the number of cases in the study and population proportions from the controls.
Population attributable risks are shown in Table 4. Assuming causality, 28% of hysterectomies were attributable to previous cesarean delivery, 24% to age 35 years or over, and 11% to parity of three or greater.
Two women died after hysterectomy, a case fatality of 0.6% (95% CI 0–1.5%). Eighty-four percent of cases were admitted to intensive care for a median of 2 days (range 1–26). Fetal/infant outcomes were known for 310 pregnancies (298 singleton and 12 twin pregnancies). There were four pregnancies in which hysterectomies were performed after second-trimester deliveries. In the remaining pregnancies, there were seven stillbirths and one neonatal death, giving a perinatal mortality rate of 25 per 1,000 total births (95% CI 7.9–42).
The U.K. Obstetric Surveillance System represents the only collection of detailed clinical information about rare conditions of pregnancy with controls using a system specifically designed for this purpose. This has important advantages over using data derived from routine data systems, which often do not include nuanced clinical information of relevance to the natural history of rare conditions and events. The U.K. Obstetric Surveillance System represents a ground-breaking extension of the principles of the Confidential Enquiry into Maternal Deaths, enabling the investigation of “near-miss” events, recognizing the fact that, in countries with well-developed health care systems where maternal deaths are rare, we need to extend our investigations beyond just death, which may not be typical of all events placing women at near risk of death.
The U.K. national incidence of peripartum hysterectomy, as estimated by this study, is 4.1 per 10,000 women delivering, or approximately 1 per 2,500 births. This estimate is compatible with the incidence identified from previous regional population-based studies in the United Kingdom, which identified a rate of 4.5 hysterectomies per 10,000 births (95% CI 2.6–6.4) in 1997–1998 in the South East Thames region8 (based on 22 cases), when the cesarean delivery rate was 18%,17 and 4.3 per 10,000 births (95% CI 3.0–5.6) in Scotland in 2003–200423 (44 cases),7 when the cesarean delivery rate was 24%.7 However, given the small size of the studies available for comparison, our results may also represent any figure between a decrease of 44% and an increase of 73% in the incidence of peripartum hysterectomy between 1997–1998 and 2005.
Our incidence estimate is also compatible with incidence rates in non-U.K. population-based studies. A recent prospective study in the Netherlands reported a rate of peripartum hysterectomy of 3.3 per 10,000 births (95% CI 2.0–4.6, 48 cases).9 Four other population-based studies conducted by retrospective database review report higher rates: 4.8 per 10,000 in Israel (95% CI 3.5–6.0),24 5.5 per 10,000 in Canada (95% CI 4.4–6.7),25 6.8 per 10,000 in Germany (95% CI 5.9–7.7),26 and 7.7 per 10,000 in the United States (95% CI 7.3–8.1).27 Only the German and U.S. studies had confidence intervals with which ours did not overlap. In view of our findings, the variations may be related to differing rates of cesarean delivery and different patterns of parity, maternal age at childbirth, and other risk factors. In view of the known limitations of retrospective database review, we cannot, however, exclude the possibility that these observed differences in incidence are simply due to differences in study methodology.
Evidence about the potential harm associated with cesarean delivery is scarce, and a recent influential National Institutes of Health consensus conference in the United States was unable to make any recommendations about how women requesting “unnecessary” cesarean delivery should be advised.14 This study has confirmed the significant risk of peripartum hysterectomy associated with prior cesarean delivery. These data provide evidence that cesarean delivery leads to a greater than seven times increase in the odds of having a peripartum hysterectomy to control hemorrhage. A similar risk was noted in a recent U.S. study using the Nationwide Inpatient Sample.27 We have also been able to identify that the risk also then extends beyond the initial cesarean delivery into subsequent deliveries; women who have had one previous cesarean delivery have more than double the risk of peripartum hysterectomy in the next pregnancy, and women who have had two or more previous cesarean deliveries have more than eighteen times the risk. This full quantification of these risks provides the evidence needed to comprehensively counsel women about the risks of primary cesarean delivery and to counsel against cesarean delivery without a specific medical indication. The mechanisms do not exist to conduct a similar study elsewhere in the world.
These findings also have implications for service planning in the light of rising cesarean delivery rates and rising age at childbirth. The most recent figures for 2004/2005 indicate that, currently, 23% of deliveries in England are cesarean deliveries.13 This rate has risen every year since 1955.13 The average age of mothers in England and Wales at the birth of their first child has risen from 28.4 to 29.4 in the past 10 years.28 Over the same time period, births to mothers over 35 years of age have increased from 11% to 19% of all births.28 Multiple births have also increased.28 Our figures suggest that 28% of peripartum hysterectomies are attributable to prior cesarean delivery, 24% to maternal age over 35 years, and 5% to twin pregnancy. These trends, if they continue, may thus be expected to lead to an increase in the numbers of women in the future requiring peripartum hysterectomy. Women who require a peripartum hysterectomy are managed with a range of other therapies to treat the associated hemorrhage as well as requiring intensive care support. The resources required to manage these women therefore extend well beyond surgical costs and can also be expected to increase. We have no information from our study about longer-term morbidity in women who have undergone peripartum hysterectomy; if significant, this will increase the resource requirements further.
We were not able to investigate the relative contribution of factors thought to be on the causal pathway between previous cesarean delivery and peripartum hysterectomy in an adjusted analysis. Thus, although we can report that women requiring hysterectomy were more likely to have abnormal placentation and we hypothesize that this is the major cause, we cannot exclude a contributory role to the requirement for hysterectomy from other factors such as preterm delivery or augmentation of labor.
In addition to quantifying the risk associated with previous cesarean delivery, we have also documented an increased risk of peripartum hysterectomy associated with other forms of uterine surgery. A small increase is associated with previous uterine instrumentation and a larger increase with both previous manual placental removal and myomectomy. These results have not been previously reported. Each of these findings has importance for the counseling of women planning pregnancy and for their care during and after delivery. However, although this was a population-based study including an estimated 780,000 births, the number of women who had had a previous myomectomy or manual placental removal was still small, and hence these risks have wide confidence intervals.
The U.K. Obstetric Surveillance System was the only source used to ascertain cases for this study. There is no routine data source through which to obtain comparable information in the United Kingdom. To check case ascertainment, at the midpoint of the study, we attempted to identify cases of peripartum hysterectomy through hospital pathology departments and intensive care units. Only one additional case was reported, which, on subsequent investigation, was found not to be a case. Although this is reassuring, we plan to undertake studies in the future to investigate the completeness of case ascertainment through the U.K. Obstetric Surveillance System more comprehensively.
The main strength of our study is that we have collected comprehensive population-based national information about women undergoing peripartum hysterectomy, together with information about control women, and, thus, we are able to quantify associated risk factors. Data collection for this study was undertaken through hospital case record review, so we have only been able to investigate factors that are adequately recorded in these records. However, before commencing the study, we did not identify any hypothesized factors that would be insufficiently well recorded to investigate using this methodology. Additionally, the information on risk factors is all recorded prospectively in obstetric case notes, before delivery or hysterectomy, so we are confident that any information bias caused by using case record review will be minimal.
Control selection is a further potential source of bias. All controls were checked to ensure that they had delivered before the case as per the selection instructions. We did not, however, undertake any further checking to ensure controls were being selected according to the instructions given, and we cannot therefore exclude the possibility of bias arising from incorrect control selection. However, it is unlikely that incorrect control selection will have introduced any systematic bias into the study because the majority of hospitals contributed only one case and her matched controls to the study. In addition, the features of the controls reflect the expected population characteristics of pregnant women in the United Kingdom, which suggests that they are an appropriate comparison group and that significant bias is unlikely to have occurred.
This study was undertaken in the setting of a country with a well-developed health care system. The results are, therefore, generalizable to all countries with similar population demographics and health care settings, including Europe, North America, and Australasia. The risks in countries with less developed health systems are likely to be different, and clinicians in those settings should interpret these results in the light of their individual circumstances.
Although fortunately a rare condition, peripartum hysterectomy nevertheless represents a catastrophic (and sometimes fatal) end to a pregnancy for any woman, regardless of whether she considers her family to be complete. This study reveals the extent of severe morbidity underlying the mortality associated with peripartum hysterectomy reported by the U.K. Confidential Enquiry into Maternal and Child Health.1 In our study, for each woman who died after a peripartum hysterectomy, more than 150 women were managed with the same procedure. This illustrates the additional value of systematically investigating “near-miss” events using systems such as the U.K. Obstetric Surveillance System to complement the in-depth confidential enquiry into deaths.
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