ライフサイエンスコーパス: hospital mortality

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

2 In-hospital mortality.

3 e hyperchloremia independently predicting in-hospital mortality.

4 ed duration of mechanical ventilation and in-hospital mortality.

5 ean IV fluids volume, and suffered higher in-hospital mortality.

6 ation myocardial infarction as well as in in-hospital mortality.

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

8 harge home but also an unexpectedly lower in-hospital mortality.

9 ing a norepinephrine shortage quarter and in-hospital mortality.

10 The primary outcome was adjusted in-hospital mortality.

11 of hypercapnia and hypercapnic acidosis with hospital mortality.

12 es of major complications, paraplegia and in-hospital mortality.

13 otic administration, and suffer increased in-hospital mortality.

14 ses, including with alternate definitions of hospital mortality.

15 e influence of dose and timing of feeding on hospital mortality.

16 The primary outcome measure was in-hospital mortality.

17 The primary outcome was in-hospital mortality.

18 derate or severe stroke and lower odds of in-hospital mortality.

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

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

21 ngth of hospital stay, ICU mortality, and in-hospital mortality.

22 Primary outcome of interest was in-hospital mortality.

23 y provided hazard ratios or only reported in-hospital mortality.

24 o a decline in multiple organ failure and in-hospital mortality.

25 n high free light chain, immunoglobulins and hospital mortality.

26 y associated with increased risk-adjusted in-hospital mortality.

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

28 h increased length of hospitalization and in-hospital mortality.

29 g, and clinician prompting did not reduce in-hospital mortality.

30 The primary endpoint was in-hospital mortality.

31 The main outcome measure was in-hospital mortality.

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

33 mes and Measures: The primary outcome was in-hospital mortality.

34 spital admissions and a 43.5% decrease in in-hospital mortality.

35 Measurement of hospital mortality.

36 180]; p = 0.02) as independent predictors of hospital mortality.

37 U and hospital, incidence of barotrauma, and hospital mortality.

38 Source control and hospital mortality.

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

40 age 2-3 AKI-UO has a high negative impact on hospital mortality.

41 owed a linear and positive relationship with hospital mortality.

42 The outcome of interest was in-hospital mortality.

43 idities, procedure use, and risk-adjusted in-hospital mortality.

44 abor, maternal readmission at 1 year, and in-hospital mortality.

45 itals during times of shortage had higher in-hospital mortality.

46 were associated with lower risk-adjusted in-hospital mortality.

47 ndicating moderate or severe stroke), and in-hospital mortality.

48 The main outcome was in-hospital mortality.

49 confidence interval, 1.159-1.805]), but not hospital, mortality.

50 ation was associated with decreased rates of hospital mortality (0.17; 95% CI, 0.03-0.86; P = .03), w

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

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

53 15.3% vs 32.8%; p < 0.0001) but had lower in-hospital mortality (13.7% vs 18.3%; p < 0.0001).

54 Hospital mortality (2.5% in the intensive group vs 4.9%

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

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

57 In-hospital mortality, 30-day mortality, and 1-year mortali

58 In-hospital mortality, 30-day mortality, and length of stay

59 proved outcomes, including lower rates of in-hospital mortality, 30-day readmission, 30-day mortality

60 iary-years of fee-for-service enrollment, in-hospital mortality, 30-day stroke or death, 30-day strok

61 Additional improvements were noted for in-hospital mortality, 30-day stroke, myocardial infarction

62 In-hospital mortality (45 [2.0] vs 37 [1.6]; P = .23) and h

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

64 cantly higher discriminative accuracy for in-hospital mortality, 6-month mortality, and return to ori

65 ls, the cooled patients tended to have lower hospital mortality (75% vs 53.4%; p = 0.26), more ventil

66 was associated with an increased rate of in-hospital mortality (9283 of 25874 patients [35.9%] vs 77

67 Three outcomes were studied: in-hospital mortality; a composite of mortality or severe n

68 2 or higher had a 3- to 14-fold increase in hospital mortality across baseline risk deciles.

69 able logistic regression was used to compare hospital mortality across both groups, adjusting for age

70 , and 0.88 [0.84-0.92], respectively) and in-hospital mortality (adjusted odds ratio [95% CI], 0.75 [

71 ntact delay was associated with increased in-hospital mortality (adjusted odds ratio for death, 1.03

72 vidence-based care was associated with lower hospital mortality (adjusted odds ratio, 0.81; 95% CI, 0

73 e the association between race/ethnicity and hospital mortality, adjusting for demographics, diagnosi

74 2 in the United States, with the adjusted in-hospital mortality after inpatient PCI being similar at

75 was associated with increased hazard for in-hospital mortality (aHR 3.48; 95% confidence interval, 1

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

77 chloremic acidosis, acute kidney injury, and hospital mortality all increased significantly as chlori

78 utes from "time-zero." Main outcomes were in-hospital mortality (all cohorts) and total direct costs

79 cause mortality; secondary endpoints were in-hospital mortality, all-cause mortality or HF rehospital

80 5% CI, 25.0%-26.6%]); unadjusted rates of in-hospital mortality also were lower for those receiving t

81 with ventricular arrhythmias and maternal in-hospital mortality, although these outcomes were rare, e

82 Hospital mortality among body mass index categories was

83 iction is a validated tool for predicting in-hospital mortality among children with respiratory failu

84 t delays in antibiotic administration and in-hospital mortality among patient encounters with communi

85 Hospital mortality among patients in an SICU after initi

86 Risk-adjusted in-hospital mortality among the renal transplant group with

87 ase volume for the receiving hospital and in-hospital mortality among transferred patients with sever

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

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

90 icians' and nurses' binary predictions of in-hospital mortality and 6-month outcomes, including morta

91 In-hospital mortality and amputation were coprimary outcome

92 egression was used to estimate risk-adjusted hospital mortality and assess the impact of 13 recommend

93 The association between in-hospital mortality and baseline covariates was estimated

94 The primary outcomes were hospital mortality and compliance with 6-hour bundle.

95 omplicated type B AD, stroke, paraplegia, in-hospital mortality and follow-up mortality appeared lowe

96 Hospital mortality and infections were primary endpoints

97 Coprimary outcomes were hospital mortality and length of stay adjusted by demogr

98 sis showed a significant decrease in ICU and hospital mortality and length of stay between 1997 and 2

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

100 Overall, overestimation of in-hospital mortality and miscalibration was more evident f

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

102 In-hospital mortality and the composite outcome of neurodev

103 The primary outcome was in-hospital mortality and the secondary outcome was median

104 The primary outcome was in-hospital mortality and the secondary outcomes included t

105 Higher %LR was associated with reduced hospital mortality and with less acute kidney injury fro

106 imated incidence during the study period, in-hospital mortality, and 1-year mortality.

107 similar rates of unplanned readmissions, in-hospital mortality, and acute myocardial infarction duri

108 sfunction was associated with higher ICU and hospital mortality, and limb muscle weakness was associa

109 temic hemorrhage, any rt-PA complication, in-hospital mortality, and modified Rankin Scale at dischar

110 timate numbers of biopsies nationwide and in-hospital mortality, and multivariable logistic regressio

111 to-treat basis for the primary outcome of in-hospital mortality, and secondary outcomes including 30-

112 assessed statistical interactions with acute hospital mortality as outcome and cohort characteristics

113 ognostic for worsening renal function and in-hospital mortality as well as mortality during follow-up

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

115 logistic regression to estimate the odds of hospital mortality based on antibiotic timing and patien

116 The adjusted odds ratio for hospital mortality based on each hour of delay in antibi

117 onary angiography, revascularization, and in-hospital mortality before and after 2010.

118 t, there was no significant difference in in-hospital mortality between centers with and without on-s

119 Adjusted risks of in-hospital mortality between New York and comparator state

120 ificant differences in the risk-adjusted, in-hospital mortality between the 2 groups in prespecified

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

122 tates was not associated with a reduction in hospital mortality beyond existing preimplementation tre

123 nts with solid tumors displayed increased in-hospital mortality (cause-specific hazard, 2.20 [95% CI,

124 KI-UO) had nearly a 3-fold increased rate of hospital mortality compared with patients without any AK

125 avenous fluids and vasopressors increased in-hospital mortality compared with usual care.

126 After medical emergency team implementation, hospital mortality continued to decrease by 6% annually

127 ht to determine whether risk-standardized in-hospital mortality could serve as an adequate proxy for

128 significantly greater discrimination for in-hospital mortality (crude AUROC, 0.753 [99% CI, 0.750-0.

129 After outlier designation, in-hospital mortality declined at outlier institutions to a

130 Risk-adjusted in-hospital mortality declined slightly in the overall coho

131 The likelihood of in-hospital mortality decreased at outlier institutions (RR

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

133 efore medical emergency team implementation, hospital mortality decreased by 6.0% annually (odds rati

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

135 esulted in a small but sustained decrease in hospital mortality, dialysis use, and length of stay.

136 In-hospital mortality did not differ between matched IVIG a

137 In-hospital mortality differences between females and males

138 However, in the public hospitals, mortality diminished significantly only in th

139 A composite of hospital mortality, discharge to hospice, or survival wi

140 ation were associated with increased odds of hospital mortality even among patients who received anti

141 otic surgeries were associated with lower in-hospital mortality, fewer complications, and shorter len

142 In-hospital mortality for females declined from 61.0% in 20

143 nd Review data contain robust information on hospital mortality for patients admitted to the ICU but

144 CDSS reduces hospital length of stay and in-hospital mortality for patients with AKI.

145 Adjusted in-hospital mortality for TV replacement was significantly

146 Improved compliance reduced hospital mortality from 4% to 2%.

147 Risk of hospital mortality from all causes (hazard ratio [HR], 1

148 Measurements included hospital mortality from all causes (total and 30 days af

149 ociation between medical emergency teams and hospital mortality have been limited and typically have

150 Secondary outcomes included hospital mortality, home discharge, 30-day readmission r

151 with frailties to examine associations with hospital mortality, hospital and ICU length of stay, and

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

153 atment does not significantly improve 28-day/hospital mortality in adult patients with sepsis.

154 biotic administration are associated with in-hospital mortality in community-acquired sepsis.

155 are the independent predictors of 50 days in-hospital mortality in culture negative neutrocytic ascit

156 te hyperchloremia independently predicted in-hospital mortality in multivariable logistic regression

157 neonates, the incidence of postoperative in-hospital mortality in neonates, and the association betw

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

159 recently developed to predict the risk of in-hospital mortality in patients undergoing transcatheter

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

161 We compared in-hospital mortality in patients who met the old definitio

162 STAL score, palliative care referral, and in-hospital mortality in patients who received RRT services

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

164 Hospital mortality in patients with NIV success and fail

165 primary aim of this study was to describe in-hospital mortality in subarachnoid hemorrhage patients r

166 Antipyretic therapy did not reduce 28-day/hospital mortality in the randomized studies (relative r

167 al membrane oxygenation score for predicting hospital mortality in veno-venous extracorporeal membran

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

169 come measures included serious morbidity, in-hospital mortality, intensive care unit admissions, and

170 e-bore catheters and its association with in-hospital mortality, length of stay, and health care cost

171 valuated rates of hospitalization for AF, in-hospital mortality, length of stay, and hospital payment

172 4 hours of admission to critical care, acute hospital mortality, length of stay, and other variables

173 requency of rehospitalization at a different hospital, mortality, length of stay, and costs during re

174 me to initial crystalloid resuscitation with hospital mortality, mechanical ventilation, ICU utilizat

175 outcomes compared included ICU mortality, in-hospital mortality, medical ICU length of stay, and post

176 Overall mortality, in-hospital mortality, metabolic outcome, graft survival, a

177 fety variables (within 30 days) included: in-hospital mortality, myocardial infarction, cerebrovascul

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

179 The primary outcome of in-hospital mortality occurred in 51 of 106 patients (48.1%

180 plementation was associated with an adjusted hospital mortality odds ratio of 0.81 (95% confidence in

181 al antimicrobial was also associated with in-hospital mortality (odds ratio = 1.05; 95% CI, 1.03-1.07

182 surgeons were more likely to have higher in-hospital mortality (odds ratio [OR], 2.09; 95% CI, 1.41-

183 oponin was associated with higher odds of in-hospital mortality (odds ratio [OR], 2.19; 95% CI, 1.88-

184 atients, 13%) had a nonsignificant impact on hospital mortality (odds ratio [OR], 2.1; P = 0.1; OR, 5

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

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

187 corticosteroids were not associated with in-hospital mortality (odds ratio, 1.41; 95% CI, 0.87-2.28;

188 s, major delay was associated with increased hospital mortality (odds ratio, 1.61; CI, 1.01-2.57) and

189 l fibrillation was associated with increased hospital mortality (odds ratio, 1.63; 95% CI, 1.01-2.63)

190 s had significantly greater risk-adjusted in-hospital mortality (odds ratio, 1.89 [95% CI, 1.79-2.00]

191 ithmically transformed) were associated with hospital mortality (odds ratio, 3.17 [95% CI, 1.12-9.00]

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

193 osition (discharge to nursing facility or in-hospital mortality, odds ratio 7.49; 95% confidence inte

194 83 had community-acquired sepsis, with an in-hospital mortality of 11%.

195 similar to patients from 2013 to 2014, with hospital mortality of 2% and with mitral regurgitation r

196 In-hospital mortality of ST-segment-elevation myocardial in

197 wever, when using the combined outcome of in-hospital mortality or discharge to hospice (risk-standar

198 However, the combined outcome of in-hospital mortality or discharge to hospice showed much b

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

200 In-hospital mortality or ICU length of stay (LOS) of 3 days

201 rimary: in-hospital mortality; secondary: in-hospital mortality or intensive care unit [ICU] length o

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

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

204 ninvasive ventilation failure (p = 0.87), in-hospital mortality (p = 0.88), 30-day readmission for ch

205 oncardiac procedure use and risk-adjusted in-hospital mortality (P<0.001 for all).

206 er TBI was associated with a reduction of in-hospital mortality (pooled OR 0.39, 95% CI: 0.27-0.56; I

207 months and were independent predictors of in-hospital mortality, predominantly down-classifying risk

208 xia were examined, and the associations with hospital mortality (primary outcome), ICU mortality, and

209 Hospital mortality rankings for older patients with AMI

210 5-32] vs 36 [14.25-40]; P = .16); and the in-hospital mortality rate (26.1% vs 22.6%, P > .99) and 90

211 %) had no evidence of AKI and had the lowest hospital mortality rate (5%).

212 The risk-adjusted in-hospital mortality rate diminished (0.2% per year) durin

213 The 50 day in-hospital mortality rate in culture negative neutrocytic

214 Overall in-hospital mortality rate was 1.6 +/- 0.9% with AD rupture

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

216 The in-hospital mortality rate was 20.4%.

217 The in-hospital mortality rate was 36% (95% CI, 30.0%-41.9%; 90

218 (2,607 vs 3,013 mL; p < 0.01), and higher in-hospital mortality rates (33% vs 11%; p < 0.01).

219 Secondary endpoints included ICU and hospital mortality rates and length of stay, time to bro

220 end was used to evaluate ICU utilization and hospital mortality rates by primary service over time.

221 This combination is associated with hospital mortality rates greater than 40%.

222 In-hospital mortality rates in renal transplant recipients

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

224 The all-cause in-hospital mortality rates were 14.4% during approved alte

225 ICU and hospital mortality rates were 27.6% and 37.3%, respectiv

226 < .001 for trend), whereas risk-adjusted in-hospital mortality remained unchanged during the study p

227 In-hospital mortality remains unchanged, but length of hosp

228 lar, while those for major complications, in-hospital mortality, retrograde type A dissection and fol

229 er-risk patients, as determined by ACTION in-hospital mortality risk score or initial troponin level.

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

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

232 the discrimination for outcomes (primary: in-hospital mortality; secondary: in-hospital mortality or

233 n is more strongly associated with increased hospital mortality than compensated hypercapnia or normo

234 sulted in greater prognostic accuracy for in-hospital mortality than did either SIRS or severe sepsis

235 These patients had higher in-hospital mortality than patients with nondetectable cyto

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

237 ationship between PCI operator volume and in-hospital mortality that persisted in risk-adjusted analy

238 The primary outcome was hospital mortality; the rate of intubation and assessmen

239 In-hospital mortality truncated at 60 days (primary outcome

240 In-hospital mortality using clinical criteria declined (-3.

241 over 72 hours and whether effects on 90-day hospital mortality varied by baseline (time 0) biomarker

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

243 In-hospital mortality was 1.7% for elective procedures but

244 Unadjusted in-hospital mortality was 1.86% for low-volume operators, 1

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

246 In-hospital mortality was 2.6%.

247 Overall, in-hospital mortality was 2.7%.

248 mor patients admitted between 2009 and 2013, hospital mortality was 26.4%.

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

250 In-hospital mortality was 33.2%, with median length of stay

251 Hospital mortality was 34.9% (95% CI, 31.4%-38.5%) for t

252 ients with ARDS were admitted to an ICU, and hospital mortality was 50.0%.

253 l malignancy admitted between 2009 and 2013, hospital mortality was 53.6%.

254 entilation failure occurred in 15.2%, and in-hospital mortality was 6.5%.

255 The in-hospital mortality was 62% for patients with IWM and 24%

256 The observed hospital mortality was 7.2%, and 30-day post-procedure m

257 Overall in-hospital mortality was 8%: 3% for patients with a qSOFA

258 In-hospital mortality was 8.8% and did not vary across the

259 Hospital mortality was 8.8% in 2011, 9.3% in 2012, and 7

260 Hospital mortality was 86.6% and 95.9%, respectively.

261 ); after adjustment for confounding factors, hospital mortality was also lower (odds ratio, 0.809 [95

262 In-hospital mortality was higher after AVR+ARE (4.3% versus

263 In-hospital mortality was higher among patients receiving o

264 the body mass index category 25.0-29.9 kg/m, hospital mortality was higher among underweight (body ma

265 In-hospital mortality was higher for patients requiring ICU

266 In-hospital mortality was higher for patients with an eleva

267 The adjusted risk of in-hospital mortality was higher for PCI procedures perform

268 rity of illness, the adjusted odds ratio for hospital mortality was higher in hypercapnic acidosis pa

269 Discrimination for in-hospital mortality was highest for NEWS (area under the

270 In-hospital mortality was lower after MINOCA than MI-CAD (1

271 In-hospital mortality was lower among infants with exposure

272 Hospital mortality was lowest among patients with severe

273 In-hospital mortality was not different (52 [5.8%] vs 85 [5

274 Decreased hospital mortality was observed primarily in patients wi

275 In-hospital mortality was significantly higher for those wi

276 The prevalence of postoperative in-hospital mortality was significantly higher in neonates

277 In-hospital mortality was significantly higher in those who

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

279 Hospital mortality was similar (12.4% vs 10.3%; p = 0.63

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

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

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

283 and Chronic Health Evaluation IV score, and hospital mortality were 63.6 years, 56.7, and 9.0%, resp

284 Independent risk factors for hospital mortality were age (odds ratio, 1.02), cardiopu

285 2009 and 2013, independent risk factors for hospital mortality were age, severity of illness, previo

286 presented, 28-day ventilator-free days, and hospital mortality were calculated in historical control

287 -7), and late (days >/=8) and the hazards of hospital mortality were evaluated between groups with mu

288 nical ventilation and ICU/hospital stay, and hospital mortality were higher in patients with dysphagi

289 aracteristics and their associations with in-hospital mortality were identified.

290 t-offs with the best prognostic accuracy for hospital mortality were identified: 5.9 L for acute kidn

291 Independent risk factors for hospital mortality were metastatic disease (odds ratio,

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

293 not associated with an increased risk of in-hospital mortality when compared with AVR (odds ratio, 1

294 dysfunctional organs, and lower adjusted in-hospital mortality when compared with the lowest-volume

295 rdiogenic shock is associated with a high in-hospital mortality, which showed a significant decline w

296 for longer than 35 days has no effect on in-hospital mortality, which suggests that current approach

297 d developing nations further showed improved hospital mortality with compliance to first-hour and sta

298 FA score had excellent discrimination for in-hospital mortality, with an area under the curve of 0.94

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

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