Empiric nasogastric decompression after pancreaticoduodenectomy is not necessary.

BACKGROUND: The aim of the present study was to evaluate the impact of routine NGT decompression after PD on postoperative outcomes in the era of an enhanced recovery after surgery (ERAS) protocol. MATERIALS AND METHODS: A retrospective review of all patients undergoing PD between January 2015 and October 2017 at our institution was performed comparing routine post-operative NGT decompression versus omission. The incidence of delayed gastric emptying, post-operative pancreatic fistula, hospital length of stay, operative time, 30-day readmission rate as well the time to first oral intake were evaluated. RESULTS: Out of 149 patients who underwent PD, 65 maintained post-operative NGT decompression while post-operative NGT decompression was omitted in 84 patients. No differences were noted in delayed gastric emptying rates (both p>0.05). The median length of stay (9 days for NGT group versus 8.5 days for no NGT group) and 30-day readmission rates (13.8% versus 15.5%, respectively) were similar (p=0.781). Compared with patients who had routine post-operative NGT placed, those who had omission of a post-operative NGT had a lower need for reinsertion, shorter time to PO intake, and a lower likelihood of extended length of stay. CONCLUSIONS: In the era of ERAS protocols, we observed no association between routine post-operative NGT decompression after PD and improved postoperative outcomes.

Late preterm delivery in women with preterm prelabour rupture of membranes.

OBJECTIVE: To estimate maternal and neonatal outcomes in women with preterm prelabour rupture of membranes (PPROM) who delivered at 34+0 to 36+6 weeks' gestation, particularly in those who had an obstetrically indicated delivery. METHODS: We conducted a population-based study of late preterm singleton births complicated by PPROM, using data from the Nova Scotia Atlee Perinatal Database from 1988 to 2006. The study cohort was categorized by type of labour (spontaneous, induced, no labour), and each group's characteristics prior to delivery, and their outcomes were compared after accounting for potential confounding variables. RESULTS: From a total population of 164 384 pregnancies, 2618 deliveries were identified as having PPROM. Among these, 2180 (83.3%) delivered between 34+0 and 36+6 weeks' gestation. Adjusted analyses showed no differences in risk between those women entering labour spontaneously (n = 1296) and those with obstetrically indicated delivery (labour induction or Caesarean section without labour, n = 698). Additional adjusted analyses evaluating only women with obstetrically indicated delivery showed that rates of chorioamnionitis (OR 0.27; 95% CI 0.08 to 0.93), composite perinatal morbidity/mortality (OR 0.39; 95% CI 0.25 to 0.62), neonatal depression at birth (OR 0.22; 95% CI 0.06 to 0.86), and respiratory distress syndrome (OR 0.17; 95% CI 0.06 to 0.47) were significantly lower in those delivering at 36 weeks (n = 458) than in those delivering at 34 to 35 weeks (n = 240). CONCLUSIONS: This large population-based study suggests that in pregnancies complicated by PPROM rates of adverse maternal and perinatal outcomes at 36 weeks' gestational age are at least comparable to those in pregnancies delivering at 34 to 35 weeks, and these rates may be further reduced by delivery after 36 completed weeks if spontaneous labour has not occurred.

How many people have had a myocardial infarction? Prevalence estimated using historical hospital data.

BACKGROUND: Health administrative data are increasingly used to examine disease occurrence. However, health administrative data are typically available for a limited number of years - posing challenges for estimating disease prevalence and incidence. The objective of this study is to estimate the prevalence of people previously hospitalized with an acute myocardial infarction (AMI) using 17 years of hospital data and to create a registry of people with myocardial infarction. METHODS: Myocardial infarction prevalence in Ontario 2004 was estimated using four methods: 1) observed hospital admissions from 1988 to 2004; 2) observed (1988 to 2004) and extrapolated unobserved events (prior to 1988) using a "back tracing" method using Poisson models; 3) DisMod incidence-prevalence-mortality model; 4) self-reported heart disease from the population-based Canadian Community Health Survey (CCHS) in 2000/2001. Individual respondents of the CCHS were individually linked to hospital discharge records to examine the agreement between self-report and hospital AMI admission. RESULTS: 170,061 Ontario residents who were alive on March 31, 2004, and over age 20 years survived an AMI hospital admission between 1988 to 2004 (cumulative incidence 1.8%). This estimate increased to 2.03% (95% CI 2.01 to 2.05) after adding extrapolated cases that likely occurred before 1988. The estimated prevalence appeared stable with 5 to 10 years of historic hospital data. All 17 years of data were needed to create a reasonably complete registry (90% of estimated prevalent cases). The estimated prevalence using both DisMod and self-reported "heart attack" was higher (2.5% and 2.7% respectively). There was poor agreement between self-reported "heart attack" and the likelihood of having an observed AMI admission (sensitivity = 63.5%, positive predictive value = 54.3%). CONCLUSION: Estimating myocardial infarction prevalence using a limited number of years of hospital data is feasible, and validity increases when unobserved events are added to observed events. The "back tracing" method is simple, reliable, and produces a myocardial infarction registry with high estimated "completeness" for jurisdictions with linked hospital data.