ライフサイエンスコーパス: in-hospital mortality

1 outcomes (length of hospital stay [LOS] and in-hospital mortality).

2 There was no significant difference in hospital mortality.

3 examination to identify patients at risk for in-hospital mortality.

4 pulmonary organ dysfunction, and substantial in-hospital mortality.

5 e incidences of PPCI, delayed treatment, and in-hospital mortality.

6 g and approach of thoracic aortic repair and in-hospital mortality.

7 ents per nurse ratio was not associated with in-hospital mortality.

8 2.64-53.61, p = 0.001) were associated with in-hospital mortality.

9 Our primary outcome measure was in-hospital mortality.

10 nfusion Assessment Method for the ICU-7, and in-hospital mortality.

11 ions (Clavien-Dindo >=III), readmission, and in-hospital mortality.

12 There was no difference in in-hospital mortality.

13 hospital lengths of stay, complications, and in-hospital mortality.

14 d an excellent negative predictive value for in-hospital mortality.

15 significantly associated with differences in in-hospital mortality.

16 y correlates with the risk of intubation and in-hospital mortality.

17 identifies patients with CS at high risk for in-hospital mortality.

18 increase) were independently associated with in-hospital mortality.

19 rium duration, higher delirium severity, and in-hospital mortality.

20 nt and hospital factors were associated with in-hospital mortality.

21 were independently associated with increased in-hospital mortality.

22 period for ED-LOS, HLOS, complications, and in-hospital mortality.

23 copically incomplete resection, or 3) 30-day/in-hospital mortality.

24 ts with STEMI and shock and its influence on in-hospital mortality.

25 quartile 4 were also associated with higher in-hospital mortality.

26 s (interquartile range, 17-40 d), with an 8% in-hospital mortality.

27 h active LSIE is an independent predictor of in-hospital mortality.

28 harge (PDD, or "against medical advice") and in-hospital mortality.

29 s significantly more accurate predictions of in-hospital mortality.

30 alaria enrolled in clinical trials and their in-hospital mortality.

31 linical cure, acute kidney injury (AKI), and in-hospital mortality.

32 es and performed a multivariable analysis of in-hospital mortality.

33 itals suffered significantly higher rates of in-hospital mortality.

34 ndently associated with an increased risk of in-hospital mortality.

35 cal ventilation or patients who evolved with in-hospital mortality.

36 hanical ventilation strategies might improve in-hospital mortality.

37 e per nurse ratio was associated with higher in-hospital mortality.

38 th delirium duration, delirium severity, and in-hospital mortality.

39 access to TAVR, TAVR utilization rates, and in-hospital mortality.

40 length of stay, hospital length of stay, and in-hospital mortality.

41 ceipt of invasive mechanical ventilation and in-hospital mortality.

42 actor-1 were not found to be associated with in-hospital mortality.

43 (aOR, 4.86 [1.92-12.28]) had higher rates of in-hospital mortality.

44 ses ED dwell times, complications, HLOS, and in-hospital mortality.

45 ently associated with risk of intubation and in-hospital mortality.

46 department physicians reported likelihood of in-hospital mortality (0-100%) by survey at hospital adm

47 In-hospital mortality (1% versus 0.4%; P=0.016) and coro

48 ificant difference between groups, including in-hospital mortality (1.7% for uncemented fixation vs 2

49 associated with a significant difference in in-hospital mortality (1.9% overlapping vs 1.6% nonoverl

50 ept for a marginally significant decrease in in-hospital mortality (-1.1%; 95% CI, -2.2% to -0.1%).

51 njury, IT was not associated with additional in-hospital mortality (11.0% for IT vs 12.1% for no IT,

52 mitted during influenza season had increased in-hospital mortality (11.0% vs. 5.8%, p = 0.024) and in

53 tracranial hemorrhage (7.7% versus 4.8%) and in-hospital mortality (12.6% versus 8.9%), but these dif

54 Neither total in-hospital mortality (13/46 [28%] versus 22/104 [21%];

55 (7.9% versus 8.6%, P=0.12), no difference in in-hospital mortality (2.2% versus 2.2% P=0.99), and a g

56 7%; 22% relative reduction [RR]; p = 0.001), in-hospital mortality (2.5% vs. 3.3%; 24% RR; p = 0.001)

57 ar revascularization had significantly lower in-hospital mortality (2.8% versus 4.0%; P=0.002), myoca

58 s after the onset of septic shock and 30-day in-hospital mortality; 2) determine whether the effect o

59 hospital length of stay (median 10 vs 11 d), in-hospital mortality (22.6% vs 29.4%), or 30-day mortal

60 Female sex was an independent predictor of in-hospital mortality (23.0% versus 21.7%; adjusted odds

61 s accompanied by significant improvements in in-hospital mortality (3.2%-0.5% for primary and 6.1%-4.

62 Secondary outcomes included in-hospital mortality, 30-day mortality from admission,

63 ength of stay (median 19 vs 8 d), and higher in-hospital mortality (33% vs 17%) (p < 0.001 for all co

64 0.67; 95% CI, 0.65-0.70) and higher rates of in-hospital mortality (4.9% versus 2.8%; odds ratio, 1.8

65 s ratio, 0.80; 95% CI, 0.76-0.84) and higher in-hospital mortality (4.9% versus 3.7%; odds ratio, 1.3

66 isk, 1.90 [95% CI, 1.63-2.22]; P<0.0001) and in hospital mortality (5.6% versus 4.2%; relative risk,

67 ESRD patients had a higher in-hospital mortality (5.1% vs. 3.4%; p < 0.01), althoug

68 rsus 22/104 [21%]; P = 0.3) nor attributable in-hospital mortality (9/46 [20%] versus 13/104 [12%]; P

69 The estimated cumulative incidence of in-hospital mortality 90 days after the initiation of EC

70 drome, the estimated cumulative incidence of in-hospital mortality 90 days after the initiation of EC

71 sting for known clinical predictors of STEMI in-hospital mortality, achievement of at least 2 STEMI c

72 ods, PCI was associated with a lower risk of in-hospital mortality across quintiles of propensity sco

73 eceiving noninvasive ventilation had similar in-hospital mortality across the ICU utilization spectru

74 n = 1,959; 44.6%) were associated with lower in-hospital mortality (adjusted hazard ratio [aHR]: 0.53

75 Higher LVSWI was associated with lower in-hospital mortality (adjusted odds ratio, 0.72 per 10

76 ulation-associated major bleeding had higher in-hospital mortality (adjusted odds ratio, 1.49; 95% CI

77 ressor was associated with increased odds of in-hospital mortality (adjusted odds ratio, 1.88; 95% CI

78 ise-comparisons <0.001) and increase in TAVR in-hospital mortality (adjusted OR, 6.13 [95% CI, 1.97-1

79 s, 95% CI 0.3-6.9), increased probability of in-hospital mortality (adjusted subdistribution hazard r

80 univariable and multivariable predictors of in-hospital mortality, adjusted for confounding with an

81 ing characteristic curves for discriminating in-hospital mortality, adjusting for baseline characteri

82 relevant hospitalization outcomes, including in-hospital mortality, after controlling for key demogra

83 ts were largely insensitive to variations in in-hospital mortality, age at baseline, or costs of reho

84 ough 31 December 2015 and analyzed regarding in-hospital mortality, age- and sex-specific distributio

85 Twenty-eight studies observed greater in-hospital mortality among all levels of prolonged ICU

86 alanced crystalloids versus saline on 30-day in-hospital mortality among critically ill adults with s

87 or assessing illness severity and predicting in-hospital mortality among critically ill patients requ

88 examined the rates of revascularization and in-hospital mortality among Medicaid beneficiaries versu

89 between the proposed SCAI staging system and in-hospital mortality among patient with heart failure a

90 need for invasive mechanical ventilation and in-hospital mortality among patients admitted with asthm

91 The rates of in-hospital mortality among pregnant women with acute st

92 To describe trends in hospital mortality and rates of discharge home among

93 monary and noncardiopulmonary complications, in-hospital mortality and 30-day readmission for HFrEF c

94 endpoints included length of hospital stay, in-hospital mortality and adverse events.

95 ial serum lactate (> 3 mmol/L) at predicting in-hospital mortality and compared these results to thos

96 ure was independently associated with higher in-hospital mortality and greater resource utilization.

97 The primary outcomes were in-hospital mortality and in-hospital major bleeding.

98 Although in-hospital mortality and major adverse cardiovascular e

99 her rates of all-cause mortality at 30 days, in-hospital mortality and mortality after discharge (p <

100 We assessed in-hospital mortality and need for postdischarge care am

101 er operator volume was associated with lower in-hospital mortality and no difference in postdischarge

102 y hemorrhage may have the greatest impact on in-hospital mortality and organ failure.

103 effects of every additional organ failure on in-hospital mortality and resource utilization were asse

104 There was a stepwise increase in in-hospital mortality and resource utilization with each

105 ased dual-energy CT variables correlate with in-hospital mortality and short-term outcomes for contus

106 dual-energy CT variables that correlate with in-hospital mortality and short-term outcomes for contus

107 Rates of in-hospital mortality and stroke, technical success, ear

108 Secondary outcomes were in-hospital mortality and stroke.

109 The main outcomes of interest were in-hospital mortality and the occurrence of de-novo vent

110 easures in RCTs such as lymph nodes harvest, in-hospital mortality, and locoregional cancer recurrenc

111 regression was used to compare the odds for in-hospital mortality, and the average marginal effects

112 19 patients, was an independent predictor of in-hospital mortality, and was associated with increased

113 y use, stimulant-only use had higher risk of in-hospital mortality (aRR 1.26, 95% CI 1.03-1.46).

114 or complication rates, clinical success, and in-hospital mortality as defined by the 2017 Heart Rhyth

115 n of increasing severity of hyponatremia and in-hospital mortality assessed using multivariable logis

116 was to describe contemporary management and in-hospital mortality associated with blunt thoracic aor

117 In-hospital mortality associated with sepsis after traum

118 zation was not significantly associated with in-hospital mortality (beta = 0.01; p = 0.05) or length

119 stay (p < 0.05) and there was no difference in hospital mortality between undocumented immigrants an

120 fference in 30-day postsurgical mortality or in-hospital mortality between the 2 groups.

121 pella use, and associated clinical outcomes (in-hospital mortality, bleeding requiring transfusion, a

122 aracterize COVID-19-associated morbidity and in-hospital mortality by race/ethnicity.

123 though small absolute difference, and higher in-hospital mortality compared with privately insured in

124 ock on presentation had a trend toward lower in-hospital mortality compared with those who presented

125 justed for patient characteristics evaluated in-hospital mortality, complications, and prolonged leng

126 In-hospital mortality declined from 62.2% in 1997 to 36.

127 Overall in-hospital mortality decreased from 22.90% pre-Affordab

128 Secondary outcomes included in-hospital mortality, diarrhea, and biochemical feature

129 In-hospital mortality did not differ (OR 2.4, P = 0.10).

130 ncidence, number of hospital admissions, and in-hospital mortality due to all-cause clinical pneumoni

131 tistics) was used to determine risk-adjusted in-hospital mortality for all distal pancreatectomies (D

132 valve surgery on rates of valve surgery and in-hospital mortality for endocarditis is not known.

133 In-hospital mortality for patients admitted to the hospi

134 In-hospital mortality for patients admitted to the hospi

135 no difference in the adjusted likelihood of in-hospital mortality for patients presenting with out-o

136 nt was an independent, negative predictor of in-hospital mortality for patients who experienced an SV

137 s, regardless of IDU status, and a reduction in-hospital mortality for patients with IE.

138 range, 3-5 d] vs 4 d [3-6 d]; p = 0.349), or in-hospital mortality (four vs three deaths; relative ri

139 In-hospital mortality from CS declined from 62.8% (1997)

140 which may be associated with a high rate of in-hospital mortality from these conditions compared wit

141 7) were independently associated with higher in-hospital mortality, greater resource utilization, and

142 ort was independently associated with higher in-hospital mortality (hazard ratio 1.89, 95% CI 1.20-2.

143 8.9 vs 10.6 +/- 13.4 d) and reduced risk of in-hospital mortality (hazard ratio, 0.47 [95% CI, 0.32-

144 ncrease, 1.14% [95% CI, 0.75%-1.53%]), lower in-hospital mortality/hospice discharge (absolute decrea

145 ease, 2.13% [95% CI, 0.81%-3.44%]) and lower in-hospital mortality/hospice discharge (absolute decrea

146 were sICH in 6.7% (449/6693) of patients and in-hospital mortality/hospice discharge in 19.6% (1326/6

147 ptomatic intracranial hemorrhage (sICH), and in-hospital mortality/hospice discharge.

148 and diabetes, no significant differences in in-hospital mortality, ICU admission, or mechanical vent

149 ed relationships between these variables and in-hospital mortality in a log-binomial model.

150 In-hospital mortality in cancer-related sepsis was 27.9%

151 ) of IFN-alpha2b was associated with reduced in-hospital mortality in comparison with no admission of

152 hyperglycemia ratio, independently predicts in-hospital mortality in critically ill patients across

153 erpretable, and highly accurate predictor of in-hospital mortality in elderly ES patients up to age 8

154 Several factors predict in-hospital mortality in fibrotic interstitial lung dise

155 pectively, the patients per nurse ratio with in-hospital mortality in ICUs.

156 Age is linearly associated with increasing in-hospital mortality in individuals receiving extracorp

157 ing age is a well-recognized risk factor for in-hospital mortality in patients receiving extracorpore

158 dictive performance of prognostic scores for in-hospital mortality in patients with aSAH.

159 In-hospital mortality in patients with SABU and SABU+SAB

160 ons between any of the 3 donor exposures and in-hospital mortality in the 3 cohorts.

161 intention-to-treat primary analyses examined in-hospital mortality in the four pairwise comparisons o

162 found between patients per nurse ratios and in-hospital mortality in The Netherlands.

163 mechanical ventilation-related predictors of in-hospital mortality included achieving early targeted

164 Unadjusted clinical predictors of in-hospital mortality included age (unit odds ratio, 1.0

165 30by3 was associated with increased odds of in-hospital mortality, irrespective of comorbidities.

166 Co-primary endpoints were in-hospital mortality, length of stay (LOS), and cost.

167 ry endpoints were antimicrobial consumption, in-hospital mortality, length of stay (LOS), and the inc

168 Secondary outcomes included an evaluation of in-hospital mortality, length of stay, infusion-related

169 n accompanied by significant improvements in in-hospital mortality, LOS, and cost.

170 gher case-fatality rates (mostly reported as in-hospital mortality) (moderate- to high-strength evide

171 Outcomes were in-hospital mortality, mortality rates based on insuranc

172 In-hospital mortality (MViV=6.3%, MViR=9%, ViMAC=18%; P=

173 ome was AKI, and secondary outcomes included in-hospital mortality, need for ventilatory support, int

174 The mean LVSWI was 38+/-14 gxmin/m(2), and in-hospital mortality occurred in 6% of patients.

175 In-hospital mortality occurred in 95 patients (3.6%), or

176 milar risk of in-hospital adverse events and in-hospital mortality (odds ratio, 0.36; 95% CI, 0.12-1.

177 cs was associated with significantly reduced in-hospital mortality (odds ratio, 0.39; 95% CI, 0.16-0.

178 ion odds ratio, 0.36; 95% CI, 0.32-0.40) and in-hospital mortality (odds ratio, 0.48; 95% CI 0.40-0.5

179 rritin levels were associated with increased in-hospital mortality (odds ratio, 1.518 per log ug/L [9

180 ion was associated with an increased risk of in-hospital mortality (odds ratio, 1.88; 95% CI, 1.59-2.

181 ratio on day 1 were associated with a higher in-hospital mortality (odds ratios, 1.19 and 1.17, respe

182 LUS implied a negative predictive value for in-hospital mortality of 98.1% (93.1-99.5%).

183 e volume and examined in relation to average in-hospital mortality of the highest volume quintile.

184 tality, 30-day mortality from admission, and in-hospital mortality or 30-day mortality post-discharge

185 Primary outcomes were in-hospital mortality or complications (major: thromboem

186 ly more likely to have a combined outcome of in-hospital mortality or discharge to hospice (25.9% ver

187 significantly associated with differences in in-hospital mortality or postoperative complication rate

188 Outcomes were assessed as in-hospital mortality or recovery.

189 .11-3.23) while older age was a predictor of in-hospital mortality (OR 4.18; 95% CI 1.94-9.04).

190 or its administration in 24 hours decreased in-hospital mortality (OR = 0.25, 95% CI [0.09-0.67]; OR

191 occurrence of paravalvular regurgitation or in-hospital mortality, or both.

192 neumonia) with each unfavorable outcome [ie, in-hospital mortality, organ failure, prolonged hospital

193 P=0.41), clinical success rate (P=0.26), and in-hospital mortality (P=0.08).

194 cardial injury was associated with increased in-hospital mortality particularly if echocardiographic

195 Hazard ratios for in-hospital mortality per transfused unit from female do

196 The outcomes evaluated were in-hospital mortality, Rancho Los Amigos scale (RLAS) sc

197 In-hospital mortality ranged from 2.1% to 4.8% in the in

198 ciated with an adjusted absolute increase in in-hospital mortality ranging from 2.2% to 15.2% compare

199 els of inflammatory markers, and the highest in-hospital mortality rate (9.5%).

200 Descriptive analyses showed that the in-hospital mortality rate for patients identified with

201 The in-hospital mortality rate was 10.0%, and at a median fo

202 l of 2859 sepsis cases were included and the in-hospital mortality rate was 14.4%.

203 Overall, the in-hospital mortality rate was 38.8% among patients with

204 In-hospital mortality rate was 51.49% in the 2886 evalua

205 The overall in-hospital mortality rate was 59.9%.

206 In-hospital mortality rate was significantly lower in st

207 he observed beneficial effects of BCG on the in-hospital mortality rate were entirely nonspecific.

208 e, need for surgical intervention and a high in-hospital mortality rate.

209 rs vs histamine-2 receptor blockers resulted in hospital mortality rates of 18.3% vs 17.5%, respectiv

210 7% vs. 2013: 56%, p < 0.001), with declining in-hospital mortality rates (1999: 64% vs. 2013: 46%; p

211 assess for changes in valve replacement and in-hospital mortality rates after the public reporting i

212 f this study was to examine whether elevated in-hospital mortality rates in lower volume hospitals ar

213 High quality of care, with in-hospital mortality rates less or equal to high-volume

214 rapy with hospital lengths of stay (LOS) and in-hospital mortality rates using linear and logistic re

215 In-hospital mortality rates were 36% (95% CI, 28%-45%),

216 Importantly, in-hospital mortality rates were almost 385-fold higher

217 nced marked decreases in greater than 14-day in-hospital mortality rates.

218 atient specific risk factors or only predict in-hospital mortality rates.

219 In-hospital mortality remained high in AMI admissions tr

220 ctivities Score per nurse ratio on day 1 and in-hospital mortality remained significant (odds ratios,

221 an approach to identify patients at risk for in-hospital mortality remains under investigation.

222 rt, the primary end point was a composite of in-hospital mortality, renal replacement therapy, or sev

223 1.31-1.47) and 4.32 (95% CI, 4.06-4.59) for in-hospital mortality, respectively.

224 This reduction in hospital mortality risk was seen across the 4 differe

225 peratively and IT does not confer additional in-hospital mortality risk.

226 The primary outcome was in-hospital mortality; secondary outcomes were invasive

227 Outcomes of interest were in-hospital mortality, temporal trends, and resource uti

228 Women had a higher unadjusted rate of in-hospital mortality than did men in both patients with

229 ated less aggressively and experience higher in-hospital mortality than men.

230 Black race was not associated with higher in-hospital mortality than white race, after adjustment

231 ertise, there was a significant reduction of in-hospital mortality to 4.8% (n = 186) after 2013 (P =

232 Outcomes of interest included in-hospital mortality, use of cardiac interventions, hos

233 End points of interest included in-hospital mortality, use of coronary angiography, perc

234 In hospital-mortality was 0%, and no major complications

235 (2%) and 7 (4%) respectively, while overall in hospital-mortality was 16 (8%).

236 eristic curve of the LUCK classification for in-hospital mortality was 0.89 (P=0.001), and of the Kil

237 Overall in-hospital mortality was 10% (1/10), peaking 25% in pat

238 ients, ICU length of stay was 8.0-10.6 days, in-hospital mortality was 10-48%, and 6-month mortality

239 ; 33% developed sepsis, 6% septic shock, and in-hospital mortality was 14%.

240 In-hospital mortality was 17% for patients with arrhythm

241 For the full cohort of patients, in-hospital mortality was 19.0%, and the median intensiv

242 Overall in-hospital mortality was 2.1%.

243 The overall median in-hospital mortality was 2.62% (interquartile range, 1.

244 Overall in-hospital mortality was 20.3% (95% CI, 18.2%-22.4%).

245 Unadjusted 30-day in-hospital mortality was 26.3% in New York State and 22

246 In-hospital mortality was 30% for venovenous extracorpor

247 In-hospital mortality was 31% for the total cohort, but

248 In-hospital mortality was 35.0% with a high viral load (

249 In-hospital mortality was 5% and 90-day mortality 8%.

250 In-hospital mortality was 50% among patients with AKI ve

251 d patients, ICU length of stay was 9.5 days, in-hospital mortality was 56%, and 6-month mortality was

252 Overall in-hospital mortality was 56%, but rates were higher whe

253 Crude in-hospital mortality was 57.7%.

254 In-hospital mortality was 8.8% for the entire patient co

255 Although in-hospital mortality was 9%, 35% of survivors demonstra

256 All-cause 30-day in-hospital mortality was 958 (4.0%) in Improving Pediat

257 ursing Activities Score per nurse ratio with in-hospital mortality was analyzed using logistic regres

258 The influence of PCI on in-hospital mortality was assessed by quintiles of prope

259 Risk for in-hospital mortality was associated with increasing SCA

260 In regression analysis, in-hospital mortality was associated with longer CPB tim

261 Lower in-hospital mortality was associated with moderate anaem

262 In-hospital mortality was evaluated for association with

263 8.53, 1.92, 2.06, 2.42, 1.75) and population in-hospital mortality was greater in England (OR 1.34, 1

264 Their in-hospital mortality was higher (35% vs 19%, P = .001),

265 Unadjusted in-hospital mortality was higher in patients who underwe

266 In the subgroup analysis, in-hospital mortality was lower in patients operated in

267 ong all ICU boarders transferred to the ICU, in-hospital mortality was lower in the electronic ICU ca

268 Compared with the Northeast, in-hospital mortality was lower in the Midwest (adjusted

269 tween clinical risk factors, biomarkers, and in-hospital mortality was modelled using Cox proportiona

270 In-hospital mortality was not associated with the use of

271 Adjusted in-hospital mortality was not different across quartiles

272 ercentiles: 3.1 to 9.6 days]; p = 0.003) and in-hospital mortality was not significantly different (6

273 In-hospital mortality was not significantly different in

274 orporeal membrane oxygenation initiation and in-hospital mortality was observed.

275 cation of variables independently predicting in-hospital mortality was performed by multivariable log

276 In-hospital mortality was significantly more common in E

277 In-hospital mortality was similar between symptomatic cr

278 The primary outcome, in-hospital mortality, was analyzed using a multivariabl

279 No differences in hospital mortality were seen between warfarin- and di

280 qSOFA >= 2 and maximum qSOFA >= 2 to predict in-hospital mortality were 33% and 69%, respectively.

281 Adjusted odds of in-hospital mortality were 39% greater in patients who m

282 Rates of in-hospital mortality were 5.2%, 18.6%, and 31.7% in pat

283 Predictors for major complications and in-hospital mortality were assessed in multivariable log

284 Age-standardized rates of operations and in-hospital mortality were calculated and mapped.

285 al length of stay (HLOS); complications; and in-hospital mortality were compared before (PRE) and aft

286 ons for MI with CS using MCS (MCS ratio) and in-hospital mortality were evaluated.

287 gic)/transient ischemic attack incidence and in-hospital mortality were extracted.

288 Odds of in-hospital mortality were higher among SARS-CoV-2 strok

289 , variables that were associated with higher in-hospital mortality were increasing age and presentati

290 Independent predictors for in-hospital mortality were renal failure (odds ratio [OR

291 patient covariates associated with increased in-hospital mortality were severity of acidosis (odds ra

292 nsive care unit, mechanical ventilation, and in-hospital mortality) were captured from electronic hea

293 ng hemostatic intervention, transfusion, and in-hospital mortality, were compared with consensus cate

294 age, and comorbidities contributed to higher in-hospital mortality, while distal perfusion cannula wa

295 ification improved Killip ability to predict in-hospital mortality with a net reclassification improv

296 In-hospital mortality with ECMO was 59.2% overall but de

297 sociated with increased odds ratio of 30-day in-hospital mortality, with the strength of association

298 Predicting in-hospital mortality within 28 days among critically il

299 The primary outcome of in-hospital mortality within 28 days occurred in 31 (9.9

300 rt, lab, and output events for prediction of in-hospital mortality without variable selection.