ライフサイエンスコーパス: in-hospital mortality

1 ence of Clostridium difficile infection, and in-hospital mortality).

2 during a norepinephrine shortage quarter and in-hospital mortality.

3 The primary outcome was adjusted in-hospital mortality.

4 rates of major complications, paraplegia and in-hospital mortality.

5 ibiotic administration, and suffer increased in-hospital mortality.

6 The primary outcome measure was in-hospital mortality.

7 The primary outcome was in-hospital mortality.

8 moderate or severe stroke and lower odds of in-hospital mortality.

9 The primary outcome was all-cause, in-hospital mortality.

10 ot ADHERE risk score was well calibrated for in-hospital mortality.

11 length of hospital stay, ICU mortality, and in-hospital mortality.

12 Primary outcome of interest was in-hospital mortality.

13 only provided hazard ratios or only reported in-hospital mortality.

14 d to a decline in multiple organ failure and in-hospital mortality.

15 ntly associated with increased risk-adjusted in-hospital mortality.

16 P = .17) were independently associated with in-hospital mortality.

17 with increased length of hospitalization and in-hospital mortality.

18 ting, and clinician prompting did not reduce in-hospital mortality.

19 The main outcome measure was in-hospital mortality.

20 The primary endpoint was in-hospital mortality.

21 The secondary outcome was all-cause in-hospital mortality.

22 tcomes and Measures: The primary outcome was in-hospital mortality.

23 iation of variables with PI and NPI and with in-hospital mortality.

24 Primary outcome was in-hospital mortality.

25 endocarditis and infective endocarditis for in-hospital mortality.

26 of the above demographic characteristics on in-hospital mortality.

27 rchical logistic regression model predicting in-hospital mortality.

28 hospital admissions and a 43.5% decrease in in-hospital mortality.

29 regression to develop a predictive model for in-hospital mortality.

30 ed the ability of characteristics to predict in-hospital mortality.

31 rwent lung transplant with 50% postoperative in-hospital mortality.

32 e and during hospitalization improved LOS or in-hospital mortality.

33 Abnormal vitals often precede in-hospital mortality.

34 tcomes, longer hospital stays, and increased in-hospital mortality.

35 ratio were all independently associated with in-hospital mortality.

36 RPIDs were not independently associated with in-hospital mortality.

37 ss of each score and the primary outcome was in-hospital mortality.

38 The outcome of interest was in-hospital mortality.

39 orbidities, procedure use, and risk-adjusted in-hospital mortality.

40 g labor, maternal readmission at 1 year, and in-hospital mortality.

41 ospitals during times of shortage had higher in-hospital mortality.

42 ds, were associated with lower risk-adjusted in-hospital mortality.

43 6 indicating moderate or severe stroke), and in-hospital mortality.

44 The main outcome was in-hospital mortality.

45 rate hyperchloremia independently predicting in-hospital mortality.

46 usted duration of mechanical ventilation and in-hospital mortality.

47 In-hospital mortality.

48 r mean IV fluids volume, and suffered higher in-hospital mortality.

49 levation myocardial infarction as well as in in-hospital mortality.

50 ion beyond 2003 did not impact risk-adjusted in-hospital mortality.

51 ischarge home but also an unexpectedly lower in-hospital mortality.

52 In-hospital mortality (0.3%) and stroke rate (1.3%) were

53 thin 7 days had significantly lower rates of in-hospital mortality (1.85%) compared with the 1,609,14

54 ho required 7 or more days of CRRT, 12 died (in-hospital mortality, 100%).

55 Transferred cases had higher in-hospital mortality (12.0% versus 6.4%; P<0.001) compa

56 e (15.3% vs 32.8%; p < 0.0001) but had lower in-hospital mortality (13.7% vs 18.3%; p < 0.0001).

57 evascularization was associated with reduced in-hospital mortality (2.34% vs. 2.73%, p < 0.001), mean

58 ts undergoing elective BAV or TAVR, rates of in-hospital mortality (2.9% versus 3.5%; P=0.60), clinic

59 h AIDS had increased severity of illness and in-hospital mortality (28.2% vs 17.8%; p < 0.0001) compa

60 Overall in-hospital mortality (3.0%) was the same in both groups

61 In-hospital mortality, 30-day mortality, and 1-year mort

62 In-hospital mortality, 30-day mortality, and length of s

63 improved outcomes, including lower rates of in-hospital mortality, 30-day readmission, 30-day mortal

64 ficiary-years of fee-for-service enrollment, in-hospital mortality, 30-day stroke or death, 30-day st

65 Additional improvements were noted for in-hospital mortality, 30-day stroke, myocardial infarct

66 In-hospital mortality (45 [2.0] vs 37 [1.6]; P = .23) an

67 up who required 7 or more days of CRRT died (in-hospital mortality, 59.1%); among the 12 patients in

68 ificantly higher discriminative accuracy for in-hospital mortality, 6-month mortality, and return to

69 3%), shock on admission (11% versus 3%), and in-hospital mortality (8% versus 3%; P<0.001 for all com

70 of ARDS, patients at risk of ARDS had higher in-hospital mortality (86/543 [16%] vs 74/232 [32%]; p<0

71 age was associated with an increased rate of in-hospital mortality (9283 of 25874 patients [35.9%] vs

72 Three outcomes were studied: in-hospital mortality; a composite of mortality or sever

73 of 2 or higher had a 3- to 14-fold increase in hospital mortality across baseline risk deciles.

74 71], and 0.88 [0.84-0.92], respectively) and in-hospital mortality (adjusted odds ratio [95% CI], 0.7

75 contact delay was associated with increased in-hospital mortality (adjusted odds ratio for death, 1.

76 des (within the same hospital stay), missing in-hospital mortality, admission post kidney transplanta

77 In-hospital mortality after elective surgical lung biops

78 Infective endocarditis and in-hospital mortality after infective endocarditis.

79 2012 in the United States, with the adjusted in-hospital mortality after inpatient PCI being similar

80 ntify patients at high risk of postoperative in-hospital mortality after resection for PHC.

81 olR was associated with increased hazard for in-hospital mortality (aHR 3.48; 95% confidence interval

82 ciate with the composite end point of AKI or in-hospital mortality (AKI/death).

83 minutes from "time-zero." Main outcomes were in-hospital mortality (all cohorts) and total direct cos

84 ll-cause mortality; secondary endpoints were in-hospital mortality, all-cause mortality or HF rehospi

85 [95% CI, 25.0%-26.6%]); unadjusted rates of in-hospital mortality also were lower for those receivin

86 ed with ventricular arrhythmias and maternal in-hospital mortality, although these outcomes were rare

87 s in HF hospitalizations, DM prevalence, and in-hospital mortality among 2.5 million discharge record

88 rediction is a validated tool for predicting in-hospital mortality among children with respiratory fa

89 ment delays in antibiotic administration and in-hospital mortality among patient encounters with comm

90 Risk-adjusted in-hospital mortality among the renal transplant group w

91 s case volume for the receiving hospital and in-hospital mortality among transferred patients with se

92 were assessed to determine the predictors of in-hospital mortality and 12-month death/severe disabili

93 who developed endocarditis had high rates of in-hospital mortality and 2-year mortality.

94 ity, the agreement between risk-standardized in-hospital mortality and 30-day mortality was modest.

95 hysicians' and nurses' binary predictions of in-hospital mortality and 6-month outcomes, including mo

96 In-hospital mortality and amputation were coprimary outc

97 The association between in-hospital mortality and baseline covariates was estima

98 e complicated type B AD, stroke, paraplegia, in-hospital mortality and follow-up mortality appeared l

99 In-hospital mortality and hospital length of stay signif

100 arge and were readmitted had higher rates of in-hospital mortality and ICU admission, longer lengths

101 We also evaluated the predictors of in-hospital mortality and length of hospitalizations.

102 apy after 48.1 hours also experienced higher in-hospital mortality and longer EBSI duration.

103 H that are associated with increased risk of in-hospital mortality and longer length of hospitalizati

104 s (odds ratio = 1.47; 95% CI = 1.30-1.66) of in-hospital mortality and lower odds (odds ratio = 0.8;

105 ed by a steady reduction in the incidence of in-hospital mortality and major amputation.

106 Overall, overestimation of in-hospital mortality and miscalibration was more eviden

107 Patients with CKD and ESRD have increased in-hospital mortality and periprocedural adverse events

108 In-hospital mortality and the composite outcome of neuro

109 The primary outcome was in-hospital mortality and the secondary outcome was medi

110 The primary outcome was in-hospital mortality and the secondary outcomes include

111 revalence in England; and in length of stay, in-hospital mortality, and 1 month readmissions for hypo

112 estimated incidence during the study period, in-hospital mortality, and 1-year mortality.

113 had similar rates of unplanned readmissions, in-hospital mortality, and acute myocardial infarction d

114 systemic hemorrhage, any rt-PA complication, in-hospital mortality, and modified Rankin Scale at disc

115 estimate numbers of biopsies nationwide and in-hospital mortality, and multivariable logistic regres

116 on-to-treat basis for the primary outcome of in-hospital mortality, and secondary outcomes including

117 prognostic for worsening renal function and in-hospital mortality as well as mortality during follow

118 We aimed to assess the risk of in-hospital mortality associated with transfusing blood

119 coronary angiography, revascularization, and in-hospital mortality before and after 2010.

120 ment, there was no significant difference in in-hospital mortality between centers with and without o

121 Adjusted risks of in-hospital mortality between New York and comparator st

122 ignificant differences in the risk-adjusted, in-hospital mortality between the 2 groups in prespecifi

123 There was no significant difference in in-hospital mortality between the intervention group and

124 d States was not associated with a reduction in hospital mortality beyond existing preimplementation

125 Secondary outcomes included in-hospital mortality, bleeding, acute kidney injury, an

126 CI, 1.5-2.4) were associated with increased in-hospital mortality but not length of hospitalization.

127 clinicians should be aware that the risk of in-hospital mortality can change quickly over the first

128 tients with solid tumors displayed increased in-hospital mortality (cause-specific hazard, 2.20 [95%

129 evascularization was associated with reduced in-hospital mortality compared to surgical revasculariza

130 ntravenous fluids and vasopressors increased in-hospital mortality compared with usual care.

131 ssessed for associations with differences in in-hospital mortality, complications, length of stay, an

132 ought to determine whether risk-standardized in-hospital mortality could serve as an adequate proxy f

133 ted significantly greater discrimination for in-hospital mortality (crude AUROC, 0.753 [99% CI, 0.750

134 After outlier designation, in-hospital mortality declined at outlier institutions t

135 Risk-adjusted in-hospital mortality declined slightly in the overall c

136 The likelihood of in-hospital mortality decreased at outlier institutions

137 Among patients that underwent PCI, in-hospital mortality decreased at outlier institutions

138 Observed in-hospital mortality decreased from 5.7% to 2.9%, and 1

139 I resulted in a small but sustained decrease in hospital mortality, dialysis use, and length of stay.

140 In-hospital mortality did not differ between matched IVI

141 In-hospital mortality differences between females and ma

142 Symptomatic intracranial hemorrhage (sICH), in-hospital mortality, discharge ambulatory status, and

143 ons were found between statin use and LOS or in-hospital mortality, even when stratified by pneumonia

144 diogenic shock and a concomitant decrease in in-hospital mortality, exceeding simultaneously observed

145 robotic surgeries were associated with lower in-hospital mortality, fewer complications, and shorter

146 Predictors of in-hospital mortality for each time cohort and long-term

147 In-hospital mortality for females declined from 61.0% in

148 f a CDSS reduces hospital length of stay and in-hospital mortality for patients with AKI.

149 In-hospital mortality for patients with P. aeruginosa BS

150 Adjusted in-hospital mortality for TV replacement was significant

151 points or more, which is associated with an in-hospital mortality greater than 10%.

152 Patients with CKD or ESRD had greater in-hospital mortality, hospital length of stay, hemorrha

153 cute myocardial infarction (MI) confers high in-hospital mortality; however, among those patients who

154 ed during a return visit to the ED had lower in-hospital mortality, ICU admission rates, and in-hospi

155 The CRT-associated in-hospital mortality improved from 1.08% in 2003 to 0.7

156 are was associated with significantly higher in-hospital mortality in an unrestricted analysis that i

157 In-hospital mortality in comatose patients resuscitated

158 ntibiotic administration are associated with in-hospital mortality in community-acquired sepsis.

159 ck are the independent predictors of 50 days in-hospital mortality in culture negative neutrocytic as

160 In-hospital mortality in HF patients with DM significant

161 Age-standardized in-hospital mortality in HF with DM also decreased signi

162 erate hyperchloremia independently predicted in-hospital mortality in multivariable logistic regressi

163 in neonates, the incidence of postoperative in-hospital mortality in neonates, and the association b

164 tes of percutaneous coronary intervention or in-hospital mortality in New York.

165 as recently developed to predict the risk of in-hospital mortality in patients undergoing transcathet

166 We observed higher rates of in-hospital mortality in patients who developed moderate

167 We compared in-hospital mortality in patients who met the old defini

168 CriSTAL score, palliative care referral, and in-hospital mortality in patients who received RRT servi

169 of the INFORM trial was to assess all-cause in-hospital mortality in patients with blood group A and

170 ragmentation predict acute kidney injury and in-hospital mortality in patients with septic shock or A

171 he primary aim of this study was to describe in-hospital mortality in subarachnoid hemorrhage patient

172 The adjusted odds of in-hospital mortality increased by 20% for each 1 hour i

173 In-hospital mortality increased in patients 80 years or

174 In-hospital mortality, intensive care unit (ICU) admissi

175 outcome measures included serious morbidity, in-hospital mortality, intensive care unit admissions, a

176 This parsimonious risk model for in-hospital mortality is a valid instrument for risk adj

177 s in hospitalization rate, hospital charges, in-hospital mortality, length of hospitalization, and co

178 arge-bore catheters and its association with in-hospital mortality, length of stay, and health care c

179 e evaluated rates of hospitalization for AF, in-hospital mortality, length of stay, and hospital paym

180 Overall procedure frequency, in-hospital mortality, major complications, and inpatien

181 ry outcomes compared included ICU mortality, in-hospital mortality, medical ICU length of stay, and p

182 Overall mortality, in-hospital mortality, metabolic outcome, graft survival

183 Safety variables (within 30 days) included: in-hospital mortality, myocardial infarction, cerebrovas

184 There was a 24% overall in-hospital mortality (n = 198).

185 The primary outcome of in-hospital mortality occurred in 51 of 106 patients (48

186 In-hospital mortality occurred in 730 patients (5.3%).

187 ained a significant independent predictor of in-hospital mortality (odds ratio 3.0; 95% confidence in

188 itial antimicrobial was also associated with in-hospital mortality (odds ratio = 1.05; 95% CI, 1.03-1

189 ume surgeons were more likely to have higher in-hospital mortality (odds ratio [OR], 2.09; 95% CI, 1.

190 troponin was associated with higher odds of in-hospital mortality (odds ratio [OR], 2.19; 95% CI, 1.

191 4 vs quartile 1, 1.05; 95% CI, 0.65-1.68) or in-hospital mortality (odds ratio quartile 4 vs quartile

192 dle was associated with higher risk-adjusted in-hospital mortality (odds ratio, 1.04 per hour; 95% co

193 ral corticosteroids were not associated with in-hospital mortality (odds ratio, 1.41; 95% CI, 0.87-2.

194 ents had significantly greater risk-adjusted in-hospital mortality (odds ratio, 1.89 [95% CI, 1.79-2.

195 afebrile remained a significant predictor of in-hospital mortality (odds ratio, 4.3; 95% CI, 2.2-8.2;

196 isposition (discharge to nursing facility or in-hospital mortality, odds ratio 7.49; 95% confidence i

197 2,683 had community-acquired sepsis, with an in-hospital mortality of 11%.

198 ected infection, the predictive validity for in-hospital mortality of SOFA was not significantly diff

199 In-hospital mortality of ST-segment-elevation myocardial

200 There were no significant differences in hospital mortality or morbidity or in late survival,

201 ly undescribed outcome measure (composite of in-hospital mortality or 30-day related readmission) and

202 However, when using the combined outcome of in-hospital mortality or discharge to hospice (risk-stan

203 However, the combined outcome of in-hospital mortality or discharge to hospice showed muc

204 the impact of using the combined outcome of in-hospital mortality or discharge to hospice.

205 In-hospital mortality or ICU length of stay (LOS) of 3 d

206 (primary: in-hospital mortality; secondary: in-hospital mortality or intensive care unit [ICU] lengt

207 e interval [CI], .74-.96) but no differences in hospital mortality (OR, 0.82; 95% CI, .58-1.15), LOS

208 s (OR, 31.8; 95% CI, 4.3-236.3) and maternal in-hospital mortality (OR, 79.1; 95% CI, 23.9-261.8).

209 Patient-level factors were associated with in-hospital mortality outcomes after elective AAA repair

210 noninvasive ventilation failure (p = 0.87), in-hospital mortality (p = 0.88), 30-day readmission for

211 f noncardiac procedure use and risk-adjusted in-hospital mortality (P<0.001 for all).

212 after TBI was associated with a reduction of in-hospital mortality (pooled OR 0.39, 95% CI: 0.27-0.56

213 6 months and were independent predictors of in-hospital mortality, predominantly down-classifying ri

214 The overall in-hospital mortality rate (10.1%) did not significantly

215 0.25-32] vs 36 [14.25-40]; P = .16); and the in-hospital mortality rate (26.1% vs 22.6%, P > .99) and

216 The risk-adjusted in-hospital mortality rate diminished (0.2% per year) du

217 The 50 day in-hospital mortality rate in culture negative neutrocyt

218 Overall in-hospital mortality rate was 1.6 +/- 0.9% with AD rupt

219 The all-cause 30-day in-hospital mortality rate was 10 in 10 000.

220 The in-hospital mortality rate was 20.4%.

221 The in-hospital mortality rate was 36% (95% CI, 30.0%-41.9%;

222 The in-hospital mortality rate was 4.6%.

223 ds (2,607 vs 3,013 mL; p < 0.01), and higher in-hospital mortality rates (33% vs 11%; p < 0.01).

224 In-hospital mortality rates in renal transplant recipien

225 The overall 3-day, in-ICU, and in-hospital mortality rates were 14.1%, 37.3%, and 41.3%

226 The all-cause in-hospital mortality rates were 14.4% during approved a

227 surgery, which remains associated with high in-hospital mortality rates, particularly in patients wi

228 Aspiration pneumonia increased in-hospital mortality (relative risk, 3.62; 95% CI, 2.65

229 ; P < .001 for trend), whereas risk-adjusted in-hospital mortality remained unchanged during the stud

230 In-hospital mortality remains unchanged, but length of h

231 imilar, while those for major complications, in-hospital mortality, retrograde type A dissection and

232 We developed a TAVR in-hospital mortality risk model and used it to quantify

233 igher-risk patients, as determined by ACTION in-hospital mortality risk score or initial troponin lev

234 ies have developed simple heart failure (HF) in-hospital mortality risk scores.

235 Crude in-hospital mortality rose (11.3 to 12.0%), whereas disc

236 Primary end point was in-hospital mortality; secondary end points included new

237 y, the discrimination for outcomes (primary: in-hospital mortality; secondary: in-hospital mortality

238 Main Outcomes and Measures: In-hospital mortality, severe morbidity (Clavien-Dindo g

239 resulted in greater prognostic accuracy for in-hospital mortality than did either SIRS or severe sep

240 These patients had higher in-hospital mortality than patients with nondetectable c

241 or more had greater prognostic accuracy for in-hospital mortality than SIRS criteria or the qSOFA sc

242 relationship between PCI operator volume and in-hospital mortality that persisted in risk-adjusted an

243 In-hospital mortality truncated at 60 days (primary outc

244 adverse kidney events were the composite of in-hospital mortality, use of RRT, and persistent elevat

245 In-hospital mortality using clinical criteria declined (

246 Overall in-hospital mortality was 0.7% for EVAR and 3.8% for OAR

247 In-hospital mortality was 1%, and CCI was 21 +/- 19.

248 In-hospital mortality was 1.7% for elective procedures b

249 Unadjusted in-hospital mortality was 1.86% for low-volume operators

250 Overall in-hospital mortality was 17.8% (55 patients): 227 patie

251 In-hospital mortality was 2.3%; 30-day mortality was 5.8

252 In-hospital mortality was 2.6%.

253 Overall, in-hospital mortality was 2.7%.

254 In-hospital mortality was 3% (5/147).

255 Postoperative in-hospital mortality was 3.4% in neonates and 0.6% in a

256 In-hospital mortality was 33.2%, with median length of s

257 In-hospital mortality was 4.3%.

258 e ventilation failure occurred in 15.2%, and in-hospital mortality was 6.5%.

259 The in-hospital mortality was 62% for patients with IWM and

260 Overall in-hospital mortality was 8%: 3% for patients with a qSO

261 In-hospital mortality was 8.8% and did not vary across t

262 In-hospital mortality was a secondary outcome.

263 In-hospital mortality was associated with a higher logis

264 While in-hospital mortality was comparable between patients wi

265 The relationship between anemia and in-hospital mortality was confirmed in our validation co

266 In-hospital mortality was higher after AVR+ARE (4.3% ver

267 In-hospital mortality was higher among patients receivin

268 In-hospital mortality was higher for patients requiring

269 In-hospital mortality was higher for patients with an el

270 The adjusted risk of in-hospital mortality was higher for PCI procedures perf

271 Discrimination for in-hospital mortality was highest for NEWS (area under t

272 In-hospital mortality was lower after MINOCA than MI-CAD

273 In-hospital mortality was lower among infants with expos

274 spitalizations for severe sepsis and sepsis, in-hospital mortality was lower among those with vs thos

275 289 [16%] died), the predictive validity for in-hospital mortality was lower for SIRS (AUROC = 0.64;

276 In-hospital mortality was not different (52 [5.8%] vs 85

277 In-hospital mortality was significantly higher for those

278 The prevalence of postoperative in-hospital mortality was significantly higher in neonat

279 In-hospital mortality was significantly higher in those

280 The rate of in-hospital mortality was significantly lower at centers

281 The risk for in-hospital mortality was similar between those who were

282 Thirty-day in-hospital mortality was the primary outcome.

283 stic end point, and prognostic prediction of in-hospital mortality was the primary prognostic end poi

284 sis for futile outcome (defined as 90-day or in-hospital mortality) was performed.

285 Procedural and in-hospital mortality were 1.4% and 8.5%, respectively.

286 Factors associated with in-hospital mortality were analyzed for OAR and EVAR usi

287 Overall morbidity and in-hospital mortality were determined in patients younge

288 characteristics and their associations with in-hospital mortality were identified.

289 terial oxygen saturation, complications, and in-hospital mortality were not different between video a

290 ion, intensive care unit length of stay, and in-hospital mortality were similar between study groups.

291 was not associated with an increased risk of in-hospital mortality when compared with AVR (odds ratio

292 ely dysfunctional organs, and lower adjusted in-hospital mortality when compared with the lowest-volu

293 cardiogenic shock is associated with a high in-hospital mortality, which showed a significant declin

294 red for longer than 35 days has no effect on in-hospital mortality, which suggests that current appro

295 The primary outcome was in-hospital mortality, which was estimated by means of a

296 Age-standardized in-hospital mortality with HF declined from 2000 to 2010

297 The overall in-hospital mortality with PA catheter use was higher th

298 pSOFA score had excellent discrimination for in-hospital mortality, with an area under the curve of 0

299 an both SIRS and severe sepsis in predicting in-hospital mortality, with an area under the receiver o

300 We hypothesized that HF scores predictive of in-hospital mortality would perform as well for early po