ライフサイエンスコーパス: hospital death

1 or hospitalization 30 days before death, in-hospital death).

2 ciated ALRI deaths (both in-hospital and non-hospital deaths).

3 ve effect of RAASi with a reduced risk of in-hospital death.

4 ciated with an increased hazard of 28-day in-hospital death.

5 icting adverse events, ICU readmissions, and hospital death.

6 was the optimal cut-off for high-risk of in-hospital death.

7 h, only 3 persons (<1%) died, including 1 in-hospital death.

8 when accounting for the competing risk of in-hospital death.

9 The primary outcome was the rate of in-hospital death.

10 ndently associated with a greater risk of in-hospital death.

11 pendently associated with a lower risk of in-hospital death.

12 pendently associated with a lower risk of in-hospital death.

13 ndently associated with an increased risk of hospital death.

14 0.43, p<0.0001) in the individual risk of in-hospital death.

15 ed with 10%-125% increased likelihoods of in-hospital death.

16 ty are associated with the risk of SSI or in-hospital death.

17 , duration of mechanical ventilation, and in-hospital death.

18 x regression analysis for risk factors of in-hospital death.

19 The primary outcome was in-hospital death.

20 ac output syndrome, infection, stroke, or in-hospital death.

21 ear was a strong independent predictor of in-hospital death.

22 801020 (-4C>T) of F12 was associated with in-hospital death.

23 en supranormal oxygen tension and risk of in-hospital death.

24 th the risk of acute complications and/or in-hospital death.

25 rongly associated with increased odds for in-hospital death.

26 r was associated with an independent risk of hospital death.

27 ified Rankin Scale (mRS) at discharge and in-hospital death.

28 l ventilation, or vasopressor therapy) or in-hospital death.

29 prevent error, drug-drug interactions and in-hospital death.

30 ion group, indicating a greater chance of in-hospital death.

31 primary outcomes were hospitalization and in-hospital death.

32 ders (0.67 [0.66-0.69]) had lower chances of hospital death.

33 uld help reduce the number of preventable in-hospital deaths.

34 ) 258, have emerged as an important cause of hospital deaths.

35 ducation for nurses could reduce preventable hospital deaths.

36 More efforts are needed to reduce hospital deaths.

37 ve mortality was 16% despite a decline in in-hospital deaths.

38 sepsis accounts for greater than 50% of all hospital deaths.

39 (4863 [44.5%]) and there were 542 (5.0%) in-hospital deaths.

40 In-hospital death (0% versus 0%), myocardial infarction (MI

41 ed ICD had a significantly higher risk of in-hospital death (0.57% [95% confidence interval {CI}, 0.4

42 57,246 bleeding events (1.7%) and 22,165 in-hospital deaths (0.65%) in 3,386,688 PCI procedures.

43 explantation had slightly higher rates of in-hospital death: 0.21% (n=26) versus 0.64% (n=80; P<0.001

44 There were 4 hospital deaths (1.3%), and overall survival at 10 and 2

45 clines were noted in out-of-hospital than in-hospital deaths (1.8% versus 4.8%; P<0.001), in older th

46 There were 11 hospital deaths (14.7%) in the GLN-PN group and 13 death

47 Incidence of in-hospital death (15.6%, 9.6%, and 3.8%; P < .001), need f

48 Increased risk was due to out-of-hospital deaths (154 long-acting opioid, 60 control deat

49 = .03) and they were more likely to avoid a hospital death (19% v 50% (95% CI, 11% to 50%; P = .004)

50 We specifically assessed in-hospital death (2.2%), hemorrhage requiring transfusion

51 In 2010, approximately 41,944 in-hospital deaths (20,212 with DVT and 21,732 with PE) occ

52 0), 7700 human metapneumovirus-associated in-hospital deaths (2600 to 48 800), and 16 100 overall (ho

53 Overall, there were 5142 (8.8%) in-hospital deaths, 2873 (4.9%) patients had intracranial h

54 ts with PFO demonstrated similar rates of in-hospital death (3.4% vs 2.6%, P = .11) and postoperative

55 s 0.2%; OR, 7.72; 95% CI, 7.47-7.98), and in-hospital death (31,885 events; 12.5% vs 1.2%; OR, 4.63;

56 ere was no difference in the incidence of in-hospital death (4.1% with abciximab vs. 3.5% with eptifi

57 ith a significant reduction in mortality (in-hospital death, 4.4%-2.3%; P=0.001) that was not apparen

58 A total of 1130 in-hospital deaths (5.1%) were observed.

59 (53.9 years) and to have a CVD-associated in-hospital death (52.8 years; n = 218).

60 Among in-hospital deaths, 52% were of cardiac causes and 44% of c

61 lizations (450 BCG, 458 controls) and 135 in-hospital deaths (56 BCG, 79 controls).

62 al admissions (543 000-1 415 000), 15 300 in-hospital deaths (5800-43 800), and up to 34 800 (13 200-

63 rction (STEMI), and had higher unadjusted in-hospital death (8.2% versus 5.7%; P<0.0001) than men.

64 Among 335 793 hospital deaths, 8274 potential donors were identified.

65 stepwise increase in the adjusted risk of in-hospital death according to decrease in global national

66 cture repair in CAHs had a higher risk of in-hospital death (adjusted odds ratio = 1.37; 95% CI, 1.01

67 lty was associated with increased risk of in-hospital death (adjusted odds ratio, 1.81 [95% CIs, 1.34

68 cord blood HSCT were at the greatest risk of hospital death (adjusted odds ratio, 4.8; 95% confidence

69 >T was associated with protection against in-hospital death (adjusted odds ratio: 0.20; 95% confidenc

70 onatremia conferred 43% increased odds of in-hospital death after adjusting for age, gender, race, bo

71 ) were the most significant predictors of in-hospital death after adjusting for age.

72 the association between HIV infection and in-hospital death after AMI or stroke.

73 Furthermore, all causes of in-hospital death after LHC were adjudicated and reported (

74 mplication were the most common causes of in-hospital death after LHC.

75 spital; and failure to rescue, defined as in-hospital death after the development of 1 or more postop

76 The risk of in-hospital death also did not differ between patients expo

77 ned sex differences in care processes and in-hospital death among 78 254 patients with AMI in 420 US

78 (i.e., body mass index) is a predictor of in-hospital death among all-comers with sepsis-providing fu

79 The odds of in-hospital death among colistin cases (compared with disch

80 diovascular disease and drug therapy with in-hospital death among hospitalized patients with Covid-19

81 ssociated with a reduction in the odds of in-hospital death among patients aged 18-49 years (adjusted

82 e is associated with an increased risk of in-hospital death among patients hospitalized with Covid-19

83 The adjusted risk of in-hospital death among patients in New York with AMI and s

84 2 is associated with dialysis requirement or hospital death among patients with ARF.

85 y of the AHRQ's 29-comorbidity index with in-hospital death among US adult hospitalizations with a di

86 The median predicted probability of in-hospital death among withdrawal of life-sustaining thera

87 of hospital discharges and of in- and out-of-hospital deaths among 35- to 74-year-old residents of 4

88 able to excellent predictive accuracy for in-hospital deaths among adult hospitalizations with VTE an

89 ; pertussis was identified in 3.7% of 137 in-hospital deaths among African cases in this age group.

90 ed number of invasive MRSA infections and in-hospital deaths among patients with MRSA in the United S

91 There were 1598 in-hospital deaths among patients with MRSA infection durin

92 onfidence interval)=0.93 (0.71, 1.22) for in-hospital death and an adjusted odds ratio (95% confidenc

93 Similarly, a decrease in the odds for in-hospital death and an increase in the speed to discharge

94 ion was associated with decreased risk of in-hospital death and death within 12 months.

95 o assess the strength of association between hospital death and explanatory variables using an adjust

96 Primary health outcomes were in-hospital death and length of stay.

97 been associated with decreasing rates of in-hospital death and major amputation rates in the United

98 s associated with higher adjusted risk of in-hospital death and major bleeding complications, althoug

99 associated with a higher hazard of 60-day in-hospital death and overweight with a lower hazard.

100 Outcomes were in-hospital death and the development of ischemic and hemor

101 timated a total of 380,001 cases; 107,880 in-hospital deaths and $26 billion in hospital-related cost

102 All-cause hospital deaths and community deaths were monitored.

103 All in-hospital deaths and CVEs after HRDM procedures were iden

104 kely to have resulted in increases in out-of-hospital deaths and long-term complications of myocardia

105 ions, intensive care unit admissions, and in-hospital deaths and low rates of referral to hospice as

106 ted human metapneumovirus-associated ALRI in-hospital deaths and overall human metapneumovirus-associ

107 ates is not explained by race differences in hospital deaths and therefore is attributable to factors

108 of Medicare spending, lower likelihood of in-hospital death, and higher use of hospice care in region

109 comes included antibiotic treatment cost, in-hospital death, and intensive care unit length of stay.

110 hypotension is common, is a predictor of in-hospital death, and is associated with diminished functi

111 nce on probability of discharge alive and in-hospital death, and multistate modelling for excess leng

112 strike periods, a high proportion of out-of-hospital deaths, and a low number of events might have l

113 jor cause of mortality, with high numbers of hospital deaths, and disproportionately affects people y

114 admission (aOR, 1.6; 95% CI, 1.1-2.3) and in-hospital death (aOR, 2.1; 95% CI, 1.1-4.0) were signific

115 e secondary endpoint was the composite of in-hospital death, aortic annulus rupture, and severe PAR.

116 After considering in-hospital death as a competing risk, AF significantly inc

117 to model time to discharge, adjusting for in-hospital death as a competing risk, and surgical risk, d

118 comorbidities as predictors and status of in-hospital death as an outcome variable.

119 peroxia was independently associated with in-hospital death as compared with either normoxia or hypox

120 come countries, low SEP is a risk factor for hospital death as well as other indicators of potentiall

121 ospital deaths were more likely than were in-hospital deaths, as were those occurring during spring/f

122 survival analysis with primary outcome of in-hospital death associated with myocardial injury.

123 there was a significantly higher risk of in-hospital death associated with use of an intravascular m

124 ivariate analysis on the relative odds of in-hospital death at each site.

125 alve (SEV, 8.7%; BEV, 13.8%; P=0.21), and in-hospital death at the time of IE episode (SEV, 35.6%; BE

126 We assessed the risk of hospital death based on quantiles of tidal volume, posit

127 identified as a potential strategy to reduce hospital deaths, because these teams respond to patients

128 Among 335,793 hospital deaths between 2005 and 2009 in Canadian provin

129 ed with prolonged mechanical ventilation and hospital death, but little is known about their risk fac

130 models were used to estimate the odds of in-hospital death by body mass index category; two-way inte

131 , 95% CI -0.63% to -0.09%, p = 0.014), while hospital deaths changed little (0.25% annually, 95% CI -

132 ntly associated with an increased risk of in-hospital death compared to normonatremia.

133 ferral surgical patients had a lower risk of hospital death compared with community patients.

134 was not associated with increased risk of in-hospital death compared with exclusive exposure to the f

135 .50) was associated with a higher risk of in-hospital death, compared with ICU-acquired dysnatremia.

136 weeks' gestation: death by 18 to 22 months; hospital death; death, intraventricular hemorrhage, or p

137 7%-0.32%/year, respectively, p<0.001), while hospital deaths declined (-1.20%; 95% CI -1.41 to -0.99/

138 Risk-adjusted hospital deaths declined -0.7 percentage points (95% CI,

139 In patients with STEMI, hospital deaths decreased by 18 percentage points (95% C

140 r, and accidental arterial puncture), and in-hospital death described with AF ablation, and we define

141 r, and accidental arterial puncture), and in-hospital deaths described with TLR, defining them by the

142 In-hospital death; development of 1 or more postoperative c

143 es of the burden of first recurrences and in-hospital deaths did not change significantly.

144 About 45% of hospital admissions and in-hospital deaths due to RSV-ALRI occur in children younge

145 We estimated the number of in-hospital deaths due to RSV-ARI by combining hCFR data wi

146 annual number of hospital admissions and in-hospital deaths due to severe acute lower respiratory in

147 The probability of in-hospital death during admissions in which individuals we

148 nade, device infection, pneumothorax, and in-hospital death even after adjustment for potential confo

149 ntly associated with an increased risk of in-hospital death, even in patients who remained normonatre

150 ,400) for those with an estimated risk of in-hospital death exceeding 15% (based on the Simplified Ac

151 definition for the numerator of POMR was in-hospital deaths following surgery (55.3%) and for the de

152 stic regression model, the odds ratio for in-hospital death for dialysis versus nondialysis patients

153 s and provided predicted probabilities of in-hospital death for each discharge and for hospital-level

154 Event criteria and estimated the risk of in-hospital death for hospital-onset sepsis versus communit

155 re that would accurately capture the risk of hospital death for patients with acute lung injury (ALI)

156 In-hospital death for patients with DS was significantly lo

157 e place of death and factors associated with hospital death for people who died from liver disease.

158 ion procedure to estimate the probability of hospital death for randomly selected patients who compri

159 The total number of in-hospital deaths for all causes was 50,788.

160 There were only 10 postoperative/hospital deaths, for a mortality of 1%.

161 We studied 358 children with RSV-related in-hospital death from 23 countries across the world, with

162 The primary end point was in-hospital death from any cause at 90 days.

163 The primary outcome was the rate of in-hospital death from any cause.

164 first recurrences, hospitalizations, and in-hospital deaths from 2011 through 2017.

165 No changes in length-of-stay or in-hospital deaths from hepatitis A over time were found, b

166 We estimated in-hospital deaths from influenza virus ALRI by combining h

167 ary outcomes included ICU admission rate, in-hospital death, functional status, and quality of life (

168 sity was associated with a higher risk of in-hospital death (hazard ratio, 1.26 [95% CI, 1.00-1.58]).

169 associated with a higher hazard of 60-day in-hospital death (hazard ratio, 1.32; 95% CI, 1.05-1.65; p

170 Other clinical variables (in-hospital death, hospital length of stay, intensive care

171 arge alive (HR, 1.07 [95% CI, .91-1.26]), or hospital death (HR, 0.99 [95% CI, .75-1.31]).

172 idence interval [CI], 0.87-0.94; P < 0.001), hospital death (HR, 1.11; 95% CI, 1.02-1.20; P = 0.01),

173 cal ventilation occurred in 2109 (27.7%), in-hospital death in 1302 (17.1%), and mechanical ventilati

174 The primary outcome was in-hospital death in a time-to-event analysis assessed at 9

175 the most important factor associated with in-hospital death in community-acquired IE (hazard ratio [H

176 scertain the extent of risk reduction for in-hospital death in COVID-19.

177 ated with lower adjusted probabilities of in-hospital death in high- and medium-spending regions (-9.

178 y better than driving pressure in predicting hospital death in patients managed with lung-protective

179 eam was associated with an increased risk of hospital death in patients transferred to the ICU from t

180 further investigation, and the low chance of hospital death in patients with alcohol-related disorder

181 an independent risk factor for all-cause in-hospital death in patients with COVID-19.

182 The high risk of hospital death in patients with sepsis, hepatorenal synd

183 regression was used to determine the odds of hospital death in relation to measures of glucose variab

184 rapy decision may contribute to premature in-hospital death in some patients who may otherwise have b

185 er surgery, the adjusted relative risk of in-hospital death in the aprotinin group was 1.78 (95% CI,

186 ultivariable analysis, the odds ratio for in-hospital death in the post- versus pre-implementation pe

187 ntly associated with an increased risk of in-hospital death in these patients.

188 ssociation of ACE inhibitors or ARBs with in-hospital death in this clinical context.

189 al admissions, and 59 600 (48 000-74 500) in-hospital deaths in children younger than 5 years.

190 There were 3217 in-hospital deaths in the KPNC cohort, 8519 in the REDS-III

191 reported in the United States with 42 339 in-hospital deaths </= 70 years from cerebrovascular accide

192 Secondary outcomes were in-hospital death, major medical and surgical complications

193 No in-hospital death, myocardial infarction, or revascularizat

194 No differences were observed for in-hospital death, myocardial infarction, or stroke or tran

195 lications related to procedure defined as in-hospital death, myocardial infarction, stroke, pericardi

196 or bleeding, or transfusion) and primary (in-hospital death/myocardial infarction) and secondary isch

197 of age, without a stress trigger, or with in-hospital death, nonfatal recurrence, embolic stroke, or

198 Although the majority of hospital deaths occur in the intensive care unit and vir

199 Hospital death occurred in 11.6%.

200 In-hospital death occurred in 127 (22.8%) patients and was

201 Four in-hospital deaths occurred (0.3%): one was considered infl

202 he precise time since death was performed on hospital deaths occurred in casualty, by medico-legal an

203 re in infants under 12 months, and 64% of in-hospital deaths occurred in infants younger than 6 month

204 About 82% of the in-hospital deaths occurred in low-income and lower-middle-

205 In-hospital deaths occurred more often among those with pre

206 Three (5%) in-hospital deaths occurred.

207 1 million in-hospital deaths (UR, 0.9-1.4 in-hospital deaths) occurred among older adults.

208 nse team was associated with reduced risk of hospital death (odds ratio, 0.657; 95% confidence interv

209 dence interval, 13.7-19.4; P<0.0001), and in-hospital death (odds ratio, 17.7; 95% confidence interva

210 ion was associated with a reduced risk of in-hospital death (odds ratio: 0.73 [95% confidence interva

211 ve was to determine the effect on risk of in-hospital death of time-dependent exposure to RBCs stored

212 urgeon-reported adverse events were low (eg, hospital deaths of 0.3%-1.0%), but data were from select

213 Most in-hospital deaths of patients with stroke, traumatic brain

214 was associated with an increased risk of in-hospital death only in those <=50 years (hazard ratio, 1

215 ociated with short-term death, defined as in-hospital death or death within 30 days of CT, whichever

216 s index category on short-term mortality (in-hospital death or discharge to hospice) adjusting for pa

217 ronic kidney disease, were followed up until hospital death or discharge.

218 Follow-up continued until in-hospital death or discharge.

219 the whole population (n=187), the rate of in-hospital death or heart transplantation was 25.5% versus

220 pump status (off-pump versus on-pump) and in-hospital death or incident renal replacement therapy (RR

221 sity were associated with higher risks of in-hospital death or mechanical ventilation (odds ratio, 1.

222 Among 7606 patients, in-hospital death or mechanical ventilation occurred in 210

223 with COVID-19, and are at higher risk of in-hospital death or mechanical ventilation, in particular,

224 ts with elevated cTn had a higher rate of in-hospital death or myocardial infarction (13.4% versus 5.

225 ociated with a reduction in the composite in-hospital death or RRT, with patients having lower preope

226 The risk-adjusted rate of in-hospital death or withdrawal from treatment was not sign

227 ransfer CT scans were not associated with in-hospital death or worsened secondary outcomes, but incre

228 buminemia was an independent predictor of in-hospital death (OR = 1.89, P = 0.014), even after adjust

229 the United States was not a predictor of in-hospital death (OR, 0.88; 95% CI, 0.60-1.30) or 30-day p

230 ing (OR, 1.63; 95% CI, 1.35-1.98) but not in-hospital death (OR, 1.15; 95% CI, 0.97-1.36).

231 For out-of-hospital deaths other than unintentional overdose (120 l

232 -sustaining treatments, hospice care, and in-hospital death over the last 6 months of life.

233 g injury were independently predictive of in-hospital death (p < .05).

234 s, respectively, for dialysis requirement or hospital death (P < 0.001).

235 s, respectively, for dialysis requirement or hospital death (P = 0.034).

236 t reclassification improvement (0.346 for in-hospital death, P = 0.004; 0.306 for 1-year death, p = 0

237 ated liver disease had the highest chance of hospital death; people who died from liver cancer were l

238 -for-performance sites (change in odds of in-hospital death per half-year period, 0.91; 95% CI, 0.84-

239 in mortality, with 17% decreased odds of in-hospital death per three-year period (P=0.012).

240 LOS, 72-hour ICU readmissions, subsequent in-hospital death, post-ICU discharge LOS, and hospital dis

241 The proportion of in-hospital deaths preceded by CPR increased, whereas the p

242 eadmission rate, and occurrence of unplanned hospital death (probability of dying in hospital after u

243 Exposed infants had a lower hospital death rate (14.2% vs 18.5% ; OR, 0.73 [95% CI,

244 d the absolute number of patients and the in-hospital death rate for crucial subcategories such as me

245 There was a decrease in the pediatric CHD in-hospital death rate from 5.1 to 2.3 per 100,000 between

246 The overall in-hospital death rate was 4.6% in discharges without ARF,

247 In-hospital death rates are lower for GUCH patients operate

248 In-hospital death rates for GUCH patients operated on by PH

249 ociated with this clinical complication, and hospital death rates in residents of a large central New

250 and contemporary trends in the incidence and hospital death rates of cardiogenic shock complicating a

251 In-hospital death rates were 32.9% in discharges with ARF t

252 of-surgery death ratio, and postoperative in-hospital death ratio.

253 In-hospital deaths, recurrent VT, and 1-year mortality were

254 The proportion of hospital deaths reduced from 71.5% in 2001 to 60.0% in 2

255 There was 1 in-hospital death (revascularization) and 1 late death (con

256 % CI, 1.54-1.82) and had a higher risk of in-hospital death (RR, 1.18; 95% CI, 1.03-1.33) but had no

257 Outcomes of interest were in-hospital death, stroke, and a modified Society of Thorac

258 Main outcome measures included in-hospital death, stroke, myocardial infarction or combine

259 ts had lower unadjusted rates of combined in-hospital death, stroke, or myocardial infarction (2.3% v

260 erators had a significantly lower rate of in-hospital death than low-volume operators (odds ratio, 0.

261 tis (1.18 [1.17-1.20]) had higher chances of hospital death than those without these respective contr

262 In-hospital death, thromboembolism, mechanical ventilation,

263 evidence about nurse staffing ratios and in-hospital death through September 2012.

264 roughly 265,000 (95% CI 160,000-450,000) in-hospital deaths took place in young children, with 99% o

265 es the potential to identify high risk of in-hospital death upon admission and supports the feasibili

266 lity, we estimated that about 1.1 million in-hospital deaths (UR, 0.9-1.4 in-hospital deaths) occurre

267 We further estimated about 14 000 in-hospital deaths (UR, 5000-50 000) related to RSV-ARI glo

268 ciated ALRI deaths based on the number of in-hospital deaths, US paediatric influenza-associated deat

269 eath and time to hospital discharge alive vs hospital death using competing risks models among patien

270 to analyze how thirty-day risk of SSI and in-hospital death varies by glucose levels and variability.

271 In-hospital death was 22.3% (n = 40), with the highest occu

272 The adjusted risk for hospital death was 3 times higher for patients with AKI

273 ic CriSTAL criteria and the prediction of in-hospital death was a secondary objective.

274 In-hospital death was analysed using multilevel logistic re

275 No increased risk of in-hospital death was found to be associated with the use o

276 ialysis patients (11.0% versus 5.0%), and in-hospital death was nearly so (21.3% versus 11.7%).

277 In-hospital death was uncommon in both groups, and change o

278 The logistic EuroSCORE predicting in-hospital death was updated using 6 methods: recalibratin

279 The odds ratios for in-hospital death were 2.4 (95% confidence interval, 2.0-2.

280 ior diagnosis of trauma within 1 year and in-hospital death were also grounds for exclusion.

281 ntly associated with an increased risk of in-hospital death were an age greater than 65 years (mortal

282 The strongest predictors of in-hospital death were cardiogenic shock (odds ratio, 6.01;

283 ital signs at presentation and subsequent in-hospital death were grouped into 2 time periods: pre-DCR

284 the clinical variables most predictive of in-hospital death were serious respiratory conditions and n

285 Significant risk factors for in-hospital death were used to develop a prediction model.

286 y, factors associated with higher risk of in-hospital death were: being aged 75-84 yrs (relative risk

287 dial infarction and ischemic stroke), and in-hospital deaths were assessed.

288 Similarly, hospital deaths were associated with a heightened risk f

289 On the other hand, in-hospital deaths were associated with pre-operative hypog

290 admissions, and 27 300 (UR 20 700-36 200) in-hospital deaths were due to RSV-ALRI.

291 of the hospital admissions and 36% of the in-hospital deaths were in infants under 6 months.

292 PM(10)-related, out-of-hospital deaths were more likely than were in-hospital d

293 In-hospital deaths were significantly higher in the hypoalb

294 In-hospital deaths were similar in statin-related diabetes

295 ive care unit patients had a similar risk of hospital death, whereas referral surgical patients had a

296 The primary outcome was hospital death with secondary outcomes of tracheostomy a

297 ignificantly associated with greater risk of hospital death, with hazard ratios ranging from 1.6 (95%

298 We defined mortality as in-hospital death within 30 days of surgery.

299 OUTCOME: Early death (in-hospital death within 4 wk of injury).

300 ted with lower likelihood of seven outcomes: hospital death within 7 days (adjusted hazard ratio, 0.3