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

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

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

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

6 The primary outcome was in-hospital death.

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

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

9 801020 (-4C>T) of F12 was associated with in-hospital death.

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

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

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

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

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

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

16 dial infarction, stroke, transfusion, and in-hospital death.

17 A similar trend was observed for in-hospital death.

18 90, p < 0.0001 for Q2 vs. Q5), but not of in-hospital death.

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

20 st-pathogen interaction are predictive of in-hospital death.

21 with ACS and is associated with increased in-hospital death.

22 antigen was independently associated with in hospital death.

23 s associated with a 56% increased risk of in-hospital death.

24 nt MI substantially increases the risk of in-hospital death.

25 depression were independent predictors of in-hospital death.

26 w probability of subsequent extubation or in-hospital death.

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

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

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

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

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

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

33 ndently associated with an increased risk of hospital death.

34 0.43, p<0.0001) in the individual risk of in-hospital death.

35 More efforts are needed to reduce hospital deaths.

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

37 here were no significant race differences in hospital deaths.

38 There were 40 in-hospital deaths.

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

40 ) 258, have emerged as an important cause of hospital deaths.

41 ducation for nurses could reduce preventable hospital deaths.

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

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

44 57,246 bleeding events (1.7%) and 22,165 in-hospital deaths (0.65%) in 3,386,688 PCI procedures.

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

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

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

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

49 going emergency CABG, there were 17 (15%) in-hospital deaths, 14 (12%) perioperative Q-wave myocardia

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

51 verity of illness (mean predicted risk of in-hospital death, 15.1%+/-21.9% vs. 11.2%+/-19.0%; p < .01

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

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

54 Although procedural success and in-hospital death (2.2% vs. 1.3%), myocardial infarction (M

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

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

57 3 days, p < 0.00005) and greater risk for in-hospital death (21.4% vs. 7.2%; p < 0.0005).

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

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

60 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;

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

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

63 Women were at higher risk for unadjusted in-hospital death (5.6% vs. 4.3%), reinfarction (4.0% vs. 3

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

65 (53.9 years) and to have a CVD-associated in-hospital death (52.8 years; n = 218).

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

67 There were 3 hospital deaths (7.1%), 2 strokes (4.8%), and 6 episodes

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

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

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

71 Thus, out-of-hospital deaths accounted for 69.2% (95% CI 69.0-69.5) o

72 on was one of the strongest predictors of in-hospital death (adjusted odds ratio 1.68; 95% confidence

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

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

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

76 Hospital deaths (adjusted risk ratio [ARR] 7.5; 95% conf

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

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

79 fusion therapy, coronary angiography, and in-hospital death after myocardial infarction, but not the

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

81 iables were significantly associated with in-hospital death: age (odds ratio [OR], 1.02 per yr), male

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

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

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

85 rapy is associated with a reduced risk of in-hospital death among high-risk, but not low-risk, patien

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

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

88 2 is associated with dialysis requirement or hospital death among patients with ARF.

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

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

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

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

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

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

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

96 As of the end of 1998, there had been no hospital deaths among the last 105 consecutive resection

97 h rare, are associated with high rates of in-hospital death and acute renal failure, often requiring

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

99 ients with CKD had a greater frequency of in-hospital death and cardiogenic shock (P<0.05 and 0.01, r

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

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

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

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

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

105 cline in CHD mortality rates was 5.3% for in-hospital deaths and 1.8% for out-of-hospital deaths (p =

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

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

108 There were no in-hospital deaths and no strokes.

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

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

111 jection fraction (EF), Q-wave infarction, in-hospital death, and initial therapy were studied.

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

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

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 dy evident that risk factors associated with hospital death are qualitatively different from risk fac

117 ant benefits of off-pump surgery in terms of hospital deaths, arrhythmias, inotropic use, use of intr

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

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

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

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

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

123 alth Evaluation III score and probability of hospital death at intensive care unit admission were 64

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

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

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

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

128 , 95% CI -0.63% to -0.09%, p = 0.014), while hospital deaths changed little (0.25% annually, 95% CI -

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

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

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

132 omen maintained a 2.3-fold higher risk of in-hospital death compared with their male counterparts (95

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

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

135 7%-0.32%/year, respectively, p<0.001), while hospital deaths declined (-1.20%; 95% CI -1.41 to -0.99/

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

137 D and SCD and to test the hypothesis that in-hospital deaths declined more than SCDs.

138 ving in nursing homes, the probability of in-hospital death decreased from 0.35 (CI, 0.23 to 0.49) to

139 ving in the community, the probability of in-hospital death decreased from 0.65 (95% CI, 0.58 to 0.71

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

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

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

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

144 f both groups believed that the number of in-hospital deaths due to preventable errors is lower than

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

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

151 >or=70 years as an independent predictor of hospital death for acute type A aortic dissection (odds

152 Our data show some predictors of hospital death for cancer patients and suggest that bett

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

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

155 were used to calculate the probability of in-hospital death for each scoring system.

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

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

158 The risk score accurately predicted in-hospital death for PCI procedures using future New York

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

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

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

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

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

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

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

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

167 years or older was a strong predictor of in-hospital death (hazard ratio, 2.5 [95% CI, 2.0 to 3.2];

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

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

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

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

172 ades, MI remains the most common cause of in-hospital death in industrialized nations.The approach to

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

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

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

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

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

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

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

180 ions of development of WRF with outcomes (in-hospital death, in-hospital complications, and length of

181 Other independent risk factors for in-hospital death included female gender, age older than 65

182 ch PSI and intensive care unit admission, in-hospital death, length of stay, and total charges.

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

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

185 Out-of-hospital deaths, measured as a proportion of all acute m

186 men in the 1985-1986 NHLBI PTCA registry, in-hospital death/MI/CABG was lower (6.0% vs. 11.6%, p < 0.

187 e 6593 cases of cardiac surgery, with 345 in-hospital deaths (mortality rate 5.23%).

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

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

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

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

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

193 Hospital death occurred in 11.6%.

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

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

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

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

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

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

200 sk groups with a predicted probability of in-hospital death of 2% as the cutoff point.

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

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

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

204 fing by registered nurses and the rate of in-hospital death or between increased staffing by licensed

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

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

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

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

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

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

211 a significant reduction in the odds of an in-hospital death or myocardial infarction in patients who

212 Significant multivariate predictors of in-hospital death or reinfarction included age, Killip clas

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

214 Our primary endpoints were hospital death or severe sequelae at discharge.

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

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

217 is, CVA was independently associated with in-hospital death (OR 7.8, 95% CI 4.2 to 14.7; p < 0.0001),

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

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

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

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

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

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

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

225 fold higher odds for dialysis requirement or hospital death (P = 0.01).

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

227 ociation with levels of ST2; furthermore, in-hospital death (P=0.003) and death/heart failure (P=0.00

228 % for in-hospital deaths and 1.8% for out-of-hospital deaths (p = 0.001).

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

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

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

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

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

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

235 percutaneous coronary intervention (PCI) (in-hospital death, Q-wave myocardial infarction, urgent or

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

237 n a prolonged SICU stay has a substantial in-hospital death rate and is costly, but the functional ou

238 During the study period, the hospital death rate decreased from 16% to 3.2%, and the

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

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

241 hagectomies, there has been a decline in the hospital death rate to less than 5%.

242 The hospital death rate was 0%, and the 30-day death rate wa

243 The overall hospital death rate was 11%.

244 The overall hospital death rate was 11.3%.

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

246 The in-hospital death rate was 9%.

247 New York City non-PICU hospital death rates also were higher than in the rest o

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

249 wide registry suggest that the incidence and hospital death rates associated with HF complicating AMI

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

251 and clinical characteristics, treatment, and hospital death rates in patients presenting with HF comp

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

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

254 nd physiologic variables were linked with in-hospital death rates using multivariable logistic regres

255 Hospital death rates were 19.5% for patients with QWMI a

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

257 Declining out-of-hospital death rates, declining incidence and recurrence

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

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

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

261 % 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

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

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

264 effects more than five times greater than in-hospital deaths, supporting the biologic plausibility of

265 oing CABG surgery are at a higher risk of in-hospital death than men, but this difference in risk dec

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

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

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

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 The outcome variable was binary, in-hospital death versus alive at discharge.

272 The risk of hospital death versus home death increased for patients

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

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

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

276 In-hospital death was analysed using multilevel logistic re

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

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

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

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

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

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 multivariable adjusted odds for in-hospital death were higher for patients with HF at prese

285 The leading causes of hospital death were pulmonary complications (45.5%) and

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

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

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

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

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

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

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

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

294 In-hospital deaths were significantly higher in the hypoalb

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

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

297 was associated with a 1.6% increased risk of hospital death, which further increased to 2.1% after in

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

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

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