Limitation of life-sustaining therapies in critically-ill patients with COVID-19: a descriptive epidemiological investigation from the COVID-ICU study

doi:10.21203/rs.3.rs-2223280/v1

Background: Limitations of life-sustaining therapies (LST) practices are frequent and vary among intensive care units (ICUs). However, scarce data were available during the COVID-19 pandemic when ICUs were under intense pressure. We aimed to investigate the prevalence, timing, modalities, and factors associated with LST decisions in critically-ill COVID-19 patients.

Methods: We did an ancillary analysis of the European multicentre COVID-ICU study, which collected data from 163 ICUs in France, Belgium and Switzerland. ICU load, a parameter reflecting stress on ICU capacities, was calculated at the patient level using daily ICU bed occupancy data from official country epidemiological reports. Mixed effects logistic regression was used to assess the association of variables with LST limitation decisions.

Results: Among 4671 severe COVID-19 patients admitted from February 25 to May 4, 2020, the prevalence of in-ICU LST limitations was 14.5%, with a nearly six-fold variability between centres. Overall 28-day cumulative incidence of LST limitations was 12.4%, which occurred at a median of 8 days (3–21). Median ICU load at the patient level was 126%. Age, clinical frailty score, and respiratory severity were associated with LST limitations, while ICU load was not. In-ICU death occurred in 74% and 95% of patients, respectively, after LST withholding and withdrawal, while median survival time was 3 days (1–11) after LST limitations.

Conclusions: Prevalence of LST limitations in critically-ill COVID-19 patients was similar to data reported pre-pandemic and not increased by stress on ICU capacities.

COVID-19

outcome

life-sustaining therapy

ethical

acute respiratory distress syndrome

critical care

In spring 2020, Europe experienced the first surge of the SARS-CoV-2 pandemic, leading to a large number of intensive care unit (ICU) admissions of severe COVID-19 patients and placing an unprecedented strain on ICUs and healthcare systems. High mortality related to the most severe forms, including acute respiratory distress syndrome (ARDS), was initially reported as reaching 40%.[1] However, mortality rates decreased over time, with a regional variability observed between centres.[2,3] Nationwide studies in the USA, the United Kingdom, France and Belgium investigated the reasons of the variability in mortality rates, with an emphasis on organizational aspects.[2–7] Importantly, findings suggested an increased COVID-19-related mortality when ICUs were overwhelmed. Facing an important surge of COVID-19 patients, facilities expanded their ICU capacities and, in some instances, scarcity of ventilators, ICU beds, staff resources, or drug use raised ethical dilemmas related to critical care resource allocation and triage.[8,9]

Ethical discussions are part of the daily process of care in the ICU where decisions to withdraw or withhold life-sustaining treatments (LST) are common. The recent Ethicus-2 study including 199 ICUs across four continents and 36 countries found an LST limitation cumulative incidence rate of 11.8% and an associated mortality of 71.9% and 88.5%, respectively, after withholding and withdrawing LST.[10] In addition, one half of deaths are preceded by LST decisions in the ICU.[11,12] Age, comorbidities, and illness severity are considered important features when discussing LST limitations,[13] but a substantial variability has been reported worldwide regarding the frequencies, modalities and timing of LST decisions, as well as between ICUs within countries.[10,14–16]

Before the COVID-19 pandemic, pressure on ICU capacity was suggested to influence both mortality[17,18] and LST decisions.[19] However, few data have been reported to date on LST decisions in critically-ill COVID-19 patients during the pandemic or when ICU capacities are facing an exceptional challenge. We sought to investigate the prevalence, timing and modalities of LST decisions in critically-ill COVID-19 patients, as well as the individual and organizational factors associated with these decisions.

Study design and patients

We did an ancillary analysis of the COVID-ICU study, a multicentre, prospective, cohort study conducted in 164 ICUs across three European countries (France, Belgium, and Switzerland), which described outcomes and risk factors of 90-day mortality of critically-ill COVID-19 patients.[1] The study was launched by the Réseau Européen de recherche en Ventilation Artificielle (REVA) and included all consecutive patients aged >16 years admitted to participating ICUs with laboratory-confirmed SARS-CoV-2 infection between February 25 and May 4, 2020. The ethics committees of the French Intensive Care Society (CE-SRLF 20-23), Belgium (2020-294), and Switzerland (BASEC #2020-00704) approved the study according to regulations for each participating country. All patients or next of kin were informed that patient data would be anonymously included in the COVID-ICU database. Patients and relatives had the possibility to decline participation in the study. In that case, data were not collected. The study followed the STROBE statement for the reporting of observational studies.[20]

All patients with laboratory-confirmed SARS-CoV-2 infection and available data regarding LST decisions and day-90 vital status were included in the study. Laboratory confirmation for SARS-Cov-2 was defined as a positive result of a real-time reverse transcriptase-polymerase chain reaction assay from either nasal or pharyngeal swabs, or lower respiratory tract samples.

Data collection

Day 1 was defined as the first day when the patient was present in the ICU at 10 am. Each day, study investigators completed a standardized electronic case report form. Data collected included baseline demographic characteristics within the first 24 h after ICU admission (day 1), comorbidities, simplified acute physiology score (SAPS-II),[21] sequential organ failure assessment (SOFA) score,[22] clinical frailty scale category,[23] date of first symptom/s, and ICU admission date. Local investigators documented the following information in a daily-expanded dataset: presence of a respiratory support device (oxygen mask, high-flow nasal cannula, noninvasive or invasive mechanical ventilation); arterial blood gases; FiO₂; PaO₂/FiO₂ ratio; use of neuromuscular blockers or corticosteroids (regardless of the indication and the dose); and standard laboratory parameters. Data were also collected on complications and organ dysfunction during the ICU stay, including acute renal failure requiring renal replacement therapy, thromboembolic complications, ventilator-associated pneumonia and cardiac arrest, as well as detailed treatment limitation decisions.

If an LST limitation was decided upon during ICU stay, investigators were asked to record in detail the following items: cardiovascular support (vasopressors, do-not-resuscitate order); ventilatory support (invasive or non-invasive, intubation, tracheotomy, respiratory device settings, FiO₂); renal replacement therapy; blood transfusion; enteral or parenteral nutrition; surgical emergency treatment; antibiotics; and intracranial pressure monitoring.

Definitions

Geographical areas (hereafter referred to as “regions”) were set as the national administrative divisions, ie, provinces for Belgium, departments for France, and cantons for Switzerland. To assess the strain on ICU capacities caused by the surge of COVID-19 patients, the ICU load was first computed at the regional level on a daily basis as:

This dynamic parameter was defined according to Bravata et al.[4] The ICU load at the patient level was finally defined as the mean ICU load in the region during the patient’s ICU stay. An ICU load of 100% reflected that all baseline ICU beds were occupied by COVID-19 patients, while an ICU load over 100% meant that the number of COVID-19 patients exceeded the baseline ICU hospitalization capacity. The number of baseline regional ICU beds before the pandemic and daily regional ICU bed occupancy during the first surge of the pandemic were based on data publicly available from official epidemiological reports on governmental websites including Public Health France and the French Ministry of Health, the Belgium Health Public Institute “Sciensano”, and the Swiss Federal Office of Public Health (see Online Data Supplement, p 4). Treatment limitations were categorized as LST withholding or withdrawal, according to the decision recorded in the daily-expanded dataset by local investigators (see Online Data Supplement, p 5). A patient with a decision of LST withdrawal after an LST withholding decision was classified in the “LST withdrawal” group.

Statistical analysis

Patients’ baseline characteristics, first 24-h in-ICU variables, treatments, organizational parameters, and ICU load at the patient level were described overall according to the following LST groups: 1) no LST; 2) LST withholding; and 3) LST withdrawal, whether or not preceded by an LST withholding decision. Continuous variables were described as medians (interquartile range [IQR]) and categorical variables as counts and percentages. Time to LST withholding and withdrawal decisions from ICU admission was estimated using a cumulative incidence function with ICU discharge and death during ICU stay as competing risks. Kaplan–Meier survival curves were plotted for the estimation of time to death from the first treatment limitation decision. In further analyses, the treatment limitation decision was dichotomized as LST withholding or withdrawal versus no limitation. Associations between variables and treatment limitation were estimated in a complete case analysis using a random intercept logistic regression model to account for the clustering of patients within centres. The following baseline variables obtained during the first 24 h in the ICU were included in the multivariable model and defined a priori (no statistical variable selection method was planned): age; gender; nursing home resident; clinical frailty scale (non-frail [1–3], pre-frail [4], frail [≥5]); body mass index ≥30 kg/m²; diabetes; hypertension; chronic heart failure; ischemic cardiomyopathy; chronic respiratory disease; chronic kidney disease; immunodepression; past hematologic disease; time between first signs and ICU admission; ICU admission period; ICU load; SOFA cardiovascular component ≥3; SOFA renal component ≥3; and ARDS severity during the first 24 h in the ICU. A sensitivity analysis was performed in centres including ≥10 patients.

Heterogeneity in withholding/withdrawal decisions between centres was investigated using meta-analytical methods to combine proportions on a logit scale and evaluated using a likelihood ratio test. Variability between centres was assessed with the tau statistic (standard deviation of the random effect).[24] This analysis was restricted to centres including 10 patients or more. Subgroup analyses were performed according to the number of patients included by centre (ie, 10-29 patients, 30-49 patients, ≥50 patients) and in centres including at least 10 patients aged 75 years or over.

Analyses were performed on a complete case analysis with no missing data imputation. Statistical significance was set at the two-sided 0.05 value for all analyses. Analyses were computed with R software, version R-4.0.2 (R Foundation for Statistical Computing, Vienna, Austria, https://www.r-project.org).

Role of the funding source

The funders of the study had no role in study design, data collection, data analysis, data interpretation, writing of the report, or the decision to submit for publication.

Study population

Among the 4746 patients included in the study from February 25 to May 4, 2020, LST status recorded in the daily dataset report form was missing for 75 patients (figure 1). Hence, 4671 patients were included in the final analysis. Median age of patients was 63 (54–70) years, and 26% were women. Eighty-two percent had at least one comorbidity and the median frailty scale was 2 (2–3). ARDS severity was mild, moderate and severe in 24%, 49% and 28% of patients, respectively, and invasive mechanical ventilation was initiated for 2866 patients (61%) during the first 24 h. All baseline characteristics of the study population are shown in table 1.

Modalities of LST withholding and withdrawal

LST limitation decisions during ICU stay occurred for 675 (14.5%) patients, including a withholding decision in 656 (14.0%) and a withdrawal decision in 297 (6.4%) patients. A withdrawal decision was mostly preceded by an LST withholding decision (278/297 [93.6%]) (table 1). LST withholding frequently included several modalities, with 82% percent of patients presenting two or more modalities of withholding (see Online Data Supplement, table E1 and table E2). A do-not-resuscitate order was the most frequent modality of LST withholding (86.6%), followed by limitations of renal replacement therapy initiation (62.8%) and an initiation or increase of vasopressors (60.2%). At the time of LST withholding decisions, patients who had a further decision of LST withdrawal included more treatment restrictions. LST withdrawal involved predominantly vasopressors (53.2%), renal replacement therapy (41.1%), and mechanical ventilation (31.6%). Extubation was decided in 24.9%.

At 28 and 90 days, the cumulative incidence of LST limitation was 12.4% and 14.8%, respectively (figure 2A). Decisions on LST limitations were taken at a median of 8 days (range 3–21) after ICU admission.

Factors associated with LST limitations

Median ICU load was 126% (range 71–187). ICU load distribution at the patient level and according to LST categories are presented in figure E1 and figure E2 (see Online Data Supplement). The multivariable model included 3051 patients (table 2). Age, clinical frailty scale score, and first 24-h respiratory failure severity were independently associated with a decision of LST limitation. Importantly, the odds ratios of the age categories ≥65 and ≤75 years and ≥75 years were 2.00 (1.51–2.64) and 8.30 (5.95–11.6), respectively, compared to patients aged <65 years (p<0.001). The decision of LST limitation was significantly associated with pre-frail and frail status compared to non-frail patients, with odds ratios of 1.61 (1.11–2.32) and 3.02 (1.89–4.82), respectively (p<0.001). By contrast, an ICU load over 100% was associated with a decreased probability of LST limitation. A sensitivity analysis yielded similar results when omitting centres including <10 patients (data not shown).

Centre characteristics and adjunct measures during ICU stay according to LST limitation status are presented in table E3 and table E4 (see Online Data Supplement).

Variability of LST limitations between centres

Of the 163 participating centres, 121 included 10 patients or more, representing a total of 4492 patients. The estimated overall proportion of patients with an LST limitation was 12.5% (95% CI 11.0–14.2; figure 3). There was a significant heterogeneity between centres, with a tau of 0.539 (likelihood-ratio test p value<0.001). Hence, it was expected that the prevalence of LST limitations in 95% of centres would lie within 4.7% and 29.1%. Similar results were observed in the subpopulation of patients aged ≥75 years and regardless to the number of patients included per centre (see Online Data Supplement, table E5, table E6, figure E3).

Outcomes

Overall, 1347 patients (29%) died within 90 days of follow-up after ICU admission. An LST withholding or withdrawal decision during ICU stay preceded death in 561 patients (42%). Of the 675 patients who experienced treatment limitation during their ICU stay, 561 (83%) died within 90 days of follow-up. In-ICU death occurred for 279 (74%) and 282 (95%) patients, respectively, after LST withholding and withdrawal. Survival time after the first treatment limitation decision was evaluated in patients with an LST decision within 14 days after ICU admission. Median survival time was 3 days (range 1–11), with a 28- and 60-day survival after a first limitation of 15.7% (95% CI 12.8–19.4) and 14.2% (95% CI 11.4–17.7), respectively (figure 2B).

This European multicentre study of 4671 patients provides the most exhaustive descriptive analysis to date on LST limitations in patients admitted to the ICU during the first surge of the COVID-19 pandemic. The global prevalence of in-ICU LST limitation decisions was 14.5%, with an important variability between centres. However, this variability was not related to the patient and/or centre characteristics analyzed in the study. Age, clinical frailty scale score, and respiratory severity were the patient characteristics most associated with decisions of LST limitations. Interestingly, while ICU load reflected an overwhelming surge of COVID-19 patients admitted to the ICU, the strain on ICU capacities was associated with a decreased probability of LST limitation. Not unexpectedly, decisions of LST withholding and withdrawal were followed by high short-term mortality and frequently preceded in-ICU death.

With regards to previously published data on LST limitations in the ICU,[10,14,15] our findings reflected a similar incidence rate and patient characteristics taken into account for ethical decision-making. A 14.5% prevalence of LST limitations is consistent with the recently reported incidence of 11.8% of all-cause ICU admissions reported in the worldwide Ethicus-2 study.[10] Older age and illness severity at ICU admission was associated with limitations of LST as already demonstrated in a general population of critically-ill patients.[14] However, the frailty score was only found to be associated with decisions of LST limitations in the ICU in the very elderly (≥80 years).[13] To the best of our knowledge, this is the first time that factors associated with LST limitations in a setting of an overwhelming surge of critically-ill patients or in a subpopulation of acute hypoxic respiratory failure patients have been identified.

The important (up to six-fold) variability of the prevalence of LST limitations observed between centres in a homogeneous population of severe COVID-19 patients represents a significant and original result of our study. Interestingly, this variability was not explained by patient or organizational characteristics of the centres. Indeed, between-ICU variability in ethical decision-making in the same range has already been reported in nationwide and international studies.[10,16,25] Some factors unrelated to individual characteristics have been identified as associated with this variability. For example, the frequency of LST limitations is higher in countries with a high gross domestic product and lower in countries where religion is important.[13] In addition, there is currently no uniform approach to the LST limitation decision-making process that could take into account all individual, relatives and social determinants, particularly in a new disease. Therefore, variability between ICUs possibly reflects differences in institutional policies.[25]

A significant variability in mortality rates was reported in several nationwide studies during the COVID-19 pandemic, with some highlighting an increased mortality rate when ICU resources were strained, but without any clear explanation of the mechanism involved.[2–7] A retrospective study of 9891 patients who died in the ICU suggested the positive association of strain on ICU capacities and a shorter time to end-of-life decision-making.[19] In the context of important ethical discussions regarding the allocation of critical care resources during the first surge of the pandemic, it appeared important to investigate the effect of ICU load on LST limitation decisions. Using the parameter proposed by Bravata et al,[4] we were able to calculate this marker reflecting strain on regional ICU resources from pre-pandemic baseline capacities and daily ICU bed occupancy data at the patient level. Despite an increased median of 126%, ICU load was associated with a lower treatment limitation probability. However, we were unable to investigate if this result was due to triage before ICU admission. Another unexplored hypothesis to explain the increased mortality in regions of high ICU strain could be related to understaffing leading to suboptimal practices, with an impact on adverse events.[18]

Of note, there are few data on LST limitations in the literature reporting an epidemiological analysis of severe COVID-19 patients during the pandemic,[26] apart from the COVIP European study, which described the characteristics of elderly patients admitted to ICUs.[27] The latter study reported a higher incidence rate of LST limitation at day 30 in COVID-19 patients compared to non-COVID-19 patients. LST limitation was associated with the frailty scale score[28] and the COVID-19 incidence rate,[29] thus suggesting that decisions of LST limitations could potentially be influenced by pressure on the healthcare system. Unfortunately, the authors did not explicitly investigate the relationship of LST limitations with strain on ICU resources.

The high mortality following decisions of LST withholding and withdrawal in our cohort of severe COVID-19 patients is similar to rates reported in the pre-pandemic literature.[10] However, when added to the prevalence of LST limitations observed and the unexplained variability across centres, these results emphasize the need to improve the reporting of LST limitations in randomized, controlled trials of COVID-19 patients managed in the ICU. Indeed, knowledge of LST decisions is of importance when assessing mortality or short-term endpoints, such as organ support-free days or duration, as both the modality and timing of LST limitations undoubtedly impact on mortality. Messika et al. demonstrated that LST limitations were rarely reported in randomized, controlled trials in critical care and that an imbalance between two groups concerning the proportion of LST decisions may affect results, particularly in open design trials.[30] To date, no randomized, controlled trial including COVID-19 patients in the ICU setting has reported rates and timing of LST limitations or proposed the standardization of treatment limitation decisions.

The strength of our study lies in the detailed description of decisions of LST limitations in the ICU during the first surge of the COVID-19 pandemic. However, the study has several limitations. First, we focused on decisions of LST limitation during ICU stay, but we are not able to provide data on triage before ICU admission. Second, our analysis was restricted to patients admitted to the ICU during the first surge. Considering likely changes of ICU practices after the first wave and a steep learning curve in the context of this new disease, we cannot exclude a subsequent different prevalence of LST limitations. However, some of our findings in the particular context of COVID-19 confirmed previous reports in a general ICU patient population. Third, as reported in the tables, some variables have missing data due to an important workload for intensivists during the first surge of the pandemic, which prevented the completion of research case report forms. Fourth, we did not investigate the variability of the timing of LST limitations between centres. Finally, we made the assumption that ICU load was the best parameter to assess ICU strain, with the hypothesis that the COVID-19-related ICU load was inferior to 100% of baseline ICU bed occupancy in France and Belgium before March 19, 2020, which is the date from when daily ICU occupancy data were communicated.

This European multicentre, prospective, observational study provides the first detailed descriptive analysis of LST limitations in a large cohort of ICU patients with severe COVID-19 during the first surge of the pandemic. The estimated prevalence of LST limitations was similar to the most recently reported pre-pandemic data among a general ICU population, despite increased pressure on ICU beds. Older age, frailty, and the severity of respiratory failure during the first 24 h were the main factors associated with decisions of LST limitations. Importantly, our results showed very significant differences in LST limitation rates between centres. LST limitations frequently preceded death, with a major impact on time of death, and this should be reported in future studies evaluating ICU mortality with severe COVID-19 or critically-ill patients.

ARDS: acute respiratory distress syndrome

ICU: intensive care unit

IQR: interquartile range

LST: life-sustaining therapies

REVA: Réseau Européen de recherche en Ventilation Artificielle

SAPS-II: simplified acute physiology score II

SOFA: sequential organ failure assessment

Ethics approval and consent to participate:

The ethics committees of the French Intensive Care Society (CE-SRLF 20-23), Belgium (2020-294), and Switzerland (BASEC #2020-00704) approved the study according to regulations for each participating country.

Consent for publication:

Not applicable.

Availability of data and materials:

The datasets used and/or analysed during the current study are available from the corresponding author on reasonable request.

Competing interests:

The authors declare that they have no competing interests.

Funding:

This study was funded by the Assistance Publique Hôpitaux de Paris Foundation through the programme “Alliance Tous Unis Contre le Virus”, Clinical Research and Development Department, French Ministry of Health, and the Private Foundation of Geneva University Hospitals. The Reseau European de recherche en Ventilation Artificielle (REVA) network received a Euro75,000 research grant from Air Liquide Healthcare. The funders of the study had no role in study design, data collection, data analysis, data interpretation, writing of the report, or the decision to submit for publication.

Author’s contributions:

SB, AP, MG, and CLT had full access to all of the data in the study and take responsibility for the integrity of the data and the accuracy of the data analysis. Concept and design: SB, AP, MG and CLT. Methodology: SB, AP, MG and CLT. Acquisition, analysis, or interpretation of data: SB, AP, MG and CLT. Drafting of the manuscript: SB, AP, MG and CLT. Critical revision of the manuscript for important intellectual content: SB, CLT, MG, EW, JP, BG, JPQ, JPR and BG. Statistical analysis: AP. Supervision: SB, JP and EW. Obtained funding: JP, CLT and SB. All authors had full access to all the data in the study, read and approved the final manuscript and had final responsibility for the decision to submit for publication.

Acknowledgments:

This study was funded by the Assistance Publique Hôpitaux de Paris Foundation through the programme “Alliance Tous Unis Contre le Virus”, Clinical Research and Development Department, French Ministry of Health, and the Private Foundation of Geneva University Hospitals. The Reseau European de recherche en Ventilation Artificielle (REVA) network received a Euro75,000 research grant from Air Liquide Healthcare.

We thank all physicians and ICU staff for their dedication in the care of our patients. We acknowledge the contributions of the Clinical Research Centre, Geneva University Hospitals and Faculty of Medicine (Isabelle Semac, Véronique Ménoni, Emmanuelle Lelong-Favre, Sophie Longchamp and Isabelle Mercier). We also acknowledge with gratitude all the French and Belgian clinical research centres, medical students, students of the Polytechnic University, and all the volunteers for their amazing help in data collection. We thank Rosemary Sudan for editorial assistance.

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Table 1. Characteristics of the included study population according to LST withholding or withdrawing during ICU stay

Variable	Missing	All (n=4671)	No limitation (n=3996)	LST withholding (n=378)	LST withdrawing (n=297)
Age (y), median (IQR)	-	63 (54, 70)	61 (53, 69)	70 (63, 76)	71 (63, 78)
Female, n (%)	33	1191 (26)	1009 (25)	108 (29)	74 (25)
Healthcare worker, n (%)	83	160 (3)	149 (4)	7 (2)	4 (1)
Nursing home resident, n (%)	47	74 (2)	46 (1)	16 (4)	12 (4)
Obesity (BMI >30 kg/m²), n (%)	336	1681 (39)	1457 (39)	134 (39)	90 (33)
SAPS II score, median (IQR)	403	37 (28, 50)	35 (27, 48)	44 (36, 56)	47 (35, 59)
SOFA score, median (IQR)	679	5 (3, 8)	4 (3, 8)	7 (4, 10)	7 (4, 10)
Hypertension, n (%)		2221 (48)	1831 (46)	224 (59)	166 (56)
Diabetes, n (%)		1271 (27)	1034 (26)	134 (35)	103 (35)
Coronary artery disease, n (%)		509 (11)	381 (10)	71 (19)	57 (19)
Chronic heart failure, n (%)		172 (4)	111 (3)	32 (8)	29 (10)
Chronic respiratory disease, n (%)	40	993 (21)	804 (20)	106 (28)	83 (28)
Immunodeficiency, n (%)	38	337 (7)	263 (7)	38 (10)	36 (12)
Chronic renal failure, n (%)	38
Yes		324 (7)	247 (6)	45 (12)	32 (11)
Chronic dialysis		112 (2)	88 (2)	15 (4)	9 (3)
Hematological malignancy, n (%)		129 (3)	93 (2)	17 (4)	19 (6)
Clinical frailty scale	465	2 (2 – 3)	2 (2 – 3)	3 (2 – 4)	3 (2 – 4)
Date of ICU admission, n (%)	167
Before March 15, 2020		n=295	225 (76)	39 (13)	31 (11)
From March 16 to 31, 2020		n=2752	2343 (85)	227 (8)	182 (7)
From April 1 to 15, 2020		n=1214	1072 (88)	75 (6)	67 (6)
After April 16, 2020		n=243	208 (86)	22 (9)	13 (5)
Time between first symptoms and ICU admission	404
< 4 days		n=421	327 (78)	50 (12)	44 (10)
4-7 days		n=1379	1138 (83)	134 (10)	107 (8)
≥ 8 days		n=2467	2200 (89)	151 (6)	116 (5)
During the first 24 h, n (%)
Standard oxygen therapy	94	1367 (29)	1202 (30)	103 (27)	62 (21)
Noninvasive ventilation	148	271 (6)	217 (5)	30 (8)	24 (8)
High-flow oxygen	162	873 (19)	767 (19)	67 (18)	39 (13)
Invasive mechanical ventilation	76	2866 (61)	2377 (60)	260 (69)	229 (77)
ARDS severity*, n (%)	412
Mild		580 (24)	488 (24)	43 (19)	49 (24)
Moderate		1197 (49)	1000 (49)	109 (47)	88 (44)
Severe		677 (28)	534 (26)	80 (34)	63 (32)
Static compliance, n (%)	341	35 (29 – 43)	35 (29 – 43)	33.6 (28 – 42)	33.3 (28 – 42)

*Data reported for patients under invasive mechanical ventilation.

LST, life-sustaining treatment; IQR, interquartile range; SAPS II, simplified acute physiology score II; BMI, body mass index; ICU, intensive care unit; SOFA, sequential organ failure assessment; ARDS, acute respiratory ddistress syndrome.

Table 2. Patient characteristics associated with LST limitations

Factor	Crude odds ratio (95% confidence interval)	Adjusted odds ratio (95% confidence interval)	P Value
Age (years)			<0.001
[16-65)	–	–
[65-75)	2.50 (1.93 to 3.23)	2.00 (1.51 to 2.65)	<0.001
[75-91]	10.19 (7.64 to 13.59)	8.28 (5.94 to 11.54)	<0.001
Female	1.07 (0.85 to 1.35)	0.91 (0.69 to 1.20)	0.507
Nursing home resident	3.86 (2.11 to 7.06)	1.41 (0.65 to 3.07)]	0.381
Clinical frailty scale score			<0.001
[1-3]	–	–
(3-4]	3.28 (2.42 to 4.45)	1.61 (1.11 to 2.32)	0.012
(4-10]	6.21 (4.27 to 9.03)	3.03 (1.89 to 4.83)	<0.001
Body mass index ≥ 30 kg/m^-2	0.88 (0.71 to 1.09)	0.92 (0.71 to 1.19)	0.529
Hypertension	1.81 (1.47 to 2.23)	1.06 (0.82 to 1.37)	0.647
Diabetes	1.64 (1.32 to 2.04)	1.39 (1.06 to 1.81)	0.016
Coronary artery disease	2.59 (1.96 to 3.41)	1.31 (0.93 to 1.85)	0.119
Chronic heart failure	4.25 (2.85 to 6.33)	1.80 (1.11 to 2.91)	0.016
Chronic respiratory disease	1.65 (1.31 to 2.09)	1.26 (0.95 to 1.65)	0.105
Immunodeficiency	1.61 (1.13 to 2.30)	1.44 (0.95 to 2.19)	0.086
Chronic renal failure			0.573
None	–	–
Yes w/o dialysis	2.32 (1.65 to 3.24)	1.13 (0.74 to 1.73)	0.578
chronic dialysis	2.21 (1.27 to 3.86)	1.43 (0.72 to 2.86)	0.311
Hematological malignancy	1.99 (1.32 to 3.01)	1.77 (1.09 to 2.88)	0.020
Period of admission			0.106
Before March 15, 2020	–	–
March 16 to 31, 2020	0.51 (0.35 to 0.73)	0.73 (0.47 to 1.14)	0.164
April 1 to 15, 2020	0.36 (0.24 to 0.55)	0.55 (0.33 to 0.92)	0.021
After April 16, 2020	0.47 (0.26 to 0.83)	0.58 (0.29 to 1.13)	0.110
Time since 1^st symptom			0.003
< 4 days	–	–
4-7 days	0.78 (0.56 to 1.08)	1.02 (0.70 to 1.50)	0.902
≥ 8 days	0.42 (0.30 to 0.58)	0.67 (0.46 to 0.98)	0.041
ICU load (%)			0.010
≤ 100	–	–
(100-150]	0.58 (0.43 to 0.78)	0.70 (0.50 to 0.99)	0.042
(150-200]	0.47 (0.34 to 0.63)	0.63 (0.44 to 0.91)	0.014
> 200	0.57 (0.41 to 0.80)	1.14 (0.75 to 1.73)	0.533
First 24-h respiratory failure severity			<0.001
Not intubated	–	–
Mild ARDS PF (200-600]	1.64 (1.21 to 2.23)	1.89 (1.27 to 2.81)	0.002
Moderate ARDS PF (100-200]	1.80 (1.37 to 2.37)	2.03 (1.40 to 2.94)	<0.001
Severe ARDS PF (0-100]	3.23 (2.37 to 4.41)	3.61 (2.42 to 5.37)	<0.001
SOFA cardiovascular ≥3	1.84 (1.49 to 2.27)	1.11 (0.83 to 1.48)	0.499
SOFA renal ≥3	1.97 (1.39 to 2.80)	1.39 (0.90 to 2.17)	0.141

LST, life-sustaining treatment; ICU, intensive care unit; SOFA, sequential organ failure assessment; ARDS, acute respiratory distress syndrome.

No competing interests reported.

Limitation of life-sustaining therapies in critically-ill patients with COVID-19: a descriptive epidemiological investigation from the COVID-ICU study

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