Open Access

Open-chest versus closed-chest cardiopulmonary resuscitation in blunt trauma: analysis of a nationwide trauma registry

  • Akira Endo1Email author,
  • Atsushi Shiraishi1, 2,
  • Yasuhiro Otomo1,
  • Makoto Tomita3,
  • Hiroki Matsui4 and
  • Kiyoshi Murata1
Critical Care201721:169

https://doi.org/10.1186/s13054-017-1759-1

Received: 20 December 2016

Accepted: 19 June 2017

Published: 3 July 2017

Abstract

Background

Although open-chest cardiopulmonary resuscitation (OCCPR) is often considered as the last salvage maneuver in critically injured patients, evidence on the effectiveness of OCCPR has been based only on the descriptive studies of limited numbers of cases or expert opinions. This study aimed to compare the effectiveness of OCCPR with that of closed-chest cardiopulmonary resuscitation (CCCPR) in an emergency department (ED).

Methods

A nationwide registry-based, retrospective cohort study was conducted. Patients with blunt trauma, undergoing cardiopulmonary resuscitation (CPR) in an ED between 2004 and 2015 were identified and divided into OCCPR and CCCPR groups. Their outcomes (survival to hospital discharge and survival over 24 hours following ED arrival) were compared with propensity score matching analysis and instrumental variable analysis.

Results

A total of 6510 patients (OCCPR, 2192; CCCPR, 4318) were analyzed. The in-hospital and 24-hour survival rates in OCCPR patients were 1.8% (40/2192) and 5.6% (123/2192), and those in CCCPR patients were 3.6% (156/4318) and 9.6% (416/4318), respectively. In the propensity score-matched subjects, OCCPR patients (n = 1804) had significantly lower odds of survival to hospital discharge (odds ratio (95% CI)) = 0.41 (0.25–0.68)) and of survival over 24 hours following ED arrival (OR (95% CI) = 0.59 (0.45–0.79)) than CCCPR patients (n = 1804). Subgroup analysis revealed that OCCPR was associated with a poorer outcome compared to CCCPR in patients with severe pelvis and lower extremity injury.

Conclusions

In this large cohort, OCCPR was associated with reduced in-hospital and 24-hour survival rates in patients with blunt trauma. Further comparisons between OCCPR and CCCPR using additional information, such as time course details in pre-hospital and ED settings, anatomical details regarding region of injury, and neurological outcomes, are necessary.

Keywords

Polytrauma Resuscitation Emergency thoracotomy Cardiac arrest Shock Registry

Background

Open-chest cardiopulmonary resuscitation (OCCPR) is often considered as one of the last salvage maneuvers in selected critically injured patients [1]; however, the procedure raises potential issues, including complications of the maneuver, cost-effectiveness, and exposure of medical staff to infection [25].

Recent guidelines recommended avoiding the indiscriminate use of emergency department (ED) thoracotomy (EDT) [68]. The indications for EDT in these guidelines are based upon a positive finding of signs of life (detectable blood pressure, respiratory or motor effort, cardiac electrical activity, or pupillary activity) or the time from onset of cardiac arrest to determine the utility of EDT. While guidelines have used the anatomical location of the injury as an indication for EDT in patients with penetrating trauma, no detailed description of the location of the injury is available for patients with blunt trauma. Although many reports have demonstrated an unfavorable outcome in patients with blunt trauma when undergoing OCCPR [911], it is important to note that there are several case reports suggesting that OCCPR may be effective in patients with blunt trauma [12, 13]. However, most of aforementioned evidence on EDT is based on descriptive studies of a limited number of patients, and the comparative effectiveness of OCCPR and closed-chest cardiopulmonary resuscitation (CCCPR) has remained unclear.

Recently, Suzuki et al. showed that patients undergoing thoracotomy within 24 hours of ED arrival had worse survival rates compared to patients undergoing CCCPR in an ED [14]. However, their results should be interpreted with caution because the study included patients undergoing thoracotomy for reasons other than for resuscitation. Furthermore, patients with cardiac arrest on ED arrival, normally requiring an evaluation of indications for OCCPR, were excluded from this study.

In developed countries, the majority of trauma patients are injured by blunt mechanisms; however, evidence on the clinical relevance of OCCPR for blunt trauma is limited compared to that on penetrating trauma [15]. The purpose of this study was to compare the effectiveness of OCCPR in the ED with that of CCCPR and to evaluate subgroups potentially benefitting from OCCPR.

Methods

Data source

The Japan Trauma Data Bank (JTDB) is a nationwide trauma registry established in 2003, and all trauma patients with an abbreviated injury scale (AIS) score ≥3 in any anatomical region are required to be registered. During the study period, the JTDB received records from 256 hospitals, of which 95% were government-approved tertiary emergency medical centers. The database includes information on injury mechanism, pre-hospital time course, patient baseline characteristics including vital signs at the scene of injury and on arriving at the ED, procedures performed, and status at hospital discharge (deceased or alive). Procedures performed in the ED are stipulated separately from other procedures performed in the operating theater after admission to the ward.

Design and settings

This was a retrospective cohort study evaluating the effectiveness of OCCPR in patients with blunt trauma, using registry data available in the JTDB. We collected data on patients with blunt injury who underwent cardiopulmonary resuscitation (CPR) in the ED. The patients were divided into two groups according to whether or not OCCPR was performed in the ED. We compared the outcomes of the two groups, adjusting for clinical background using propensity score matching analysis. We also evaluated the potential benefits and drawbacks of OCCPR compared with CCCPR among subgroups. The ethics committee of Tokyo Medical and Dental University approved this study (#2192).

Study population

We included patients with blunt trauma who received CPR in an ED from January 2004 to December 2015. We excluded patients with an AIS score of 6 because, by definition, these injuries are fatal (i.e. anatomically unsalvageable injury). Patients with a missing AIS score in any anatomical region were excluded to avoid analyzing the patients who potentially had an anatomically unsalvageable injury. Patients transferred from another hospital were also excluded.

Data collection

We collected the following patient information from the JTDB: age, sex, year of injury, pre-hospital vital signs (systolic blood pressure, heart rate, and respiratory rate), time from emergency medical service (EMS) dispatch to ED arrival, pre-hospital treatment by paramedics (chest compression and defibrillation), vital signs (systolic blood pressure, heart rate, and respiratory rate) and Glasgow coma scale (GCS) score on ED arrival, AIS score for each region, injury severity score (ISS), resuscitation method (OCCPR or CCCPR), status at hospital discharge (survival or death), and time to death or hospital discharge. In addition, we collected hospital information, including the annual number of registered patients, OCCPR cases, and unexpected survivors defined as patients who had survived with a probability of survival based on the trauma and injury severity score (TRISS) <0.5 [16].

Definitions and outcomes

Cardiac arrest was defined as a registered systolic blood pressure = 0 mmHg based on the JTDB data registration instructions, which say that systolic blood pressure in a patient whose pulse is not palpable should be registered as 0 mmHg even though actual blood pressure could not be 0 mmHg (i.e. cardiac arrest). The primary study outcome was survival to hospital discharge and the secondary study outcome was survival over 24 hours following arrival at the ED.

Statistical analysis

Statistical analysis was performed using R 3.2.3 (R Foundation for Statistical Computing, Vienna, Austria). Missing mechanism of data in the naïve dataset were assumed clinically as missing at random (Additional file 1), so that missing data on the collected variables were complemented by the method of multivariate imputation by chained equations with 15 iterations using the package “mice” [17] and 51 datasets were produced. Descriptive statistics were used to display categorical variables as counts and percentages, and numeric or ordered variables as medians and 25th–75th percentiles, after pooling all the imputed datasets into one dataset. Predictive statistics were used to display the estimators as point estimation and 95% confidence intervals (CI) integrated across the imputed datasets, based on Rubin’s rule [18].

We used propensity score matching to compare the outcomes between the OCCPR group and the CCCPR group. The propensity score for predicting OCCPR was calculated by logistic regression analysis using variables pertaining to the year of injury, patient factors (age and sex), time from EMS dispatch to ED arrival, mean number of unexpected survivors per year in the treating hospital that the patient was transferred to, vital signs at the scene of injury (systolic blood pressure, heart rate, and respiratory rate), whether or not cardiac arrest at the scene of injury was observed, vital signs (systolic blood pressure, heart rate, respiratory rate, and body temperature) and GCS on ED arrival, whether or not cardiac arrest was observed on ED arrival, AIS score of each region, and ISS. Propensity score matching extracted 1:1 matched pairs of subjects from the OCCPR group and the CCCPR group using the values of the logit-transformed propensity score calculated for each imputed dataset and averaged across the datasets. Match balance between the two groups was assessed by the absolute standardized mean difference of all the variables, and values lower than 0.1 were regarded as acceptable. To achieve this match balance, the caliper width of matching was set at 0.01. Intergroup comparison of the outcomes with propensity-score-matched subjects was performed using the chi-square test. Survival curves were constructed using Kaplan-Meier estimates for the propensity-score-matched subjects and were compared using a log-rank test.

The primary outcome was compared in the propensity-score-matched cohort across subgroups stratified according to sex, age (<50 or ≥50 years), time from EMS dispatch to ED arrival (<30 or ≥30 min), systolic blood pressure on ED arrival (<60 or ≥60 mmHg), whether or not cardiac arrest was observed at the scene of injury, whether or not cardiac arrest was observed on ED arrival, ISS (<30 or ≥30), and AIS score of head, chest, abdomen, and pelvis and lower extremities (0–2 or 3–5). For each subgroup, logistic regression analysis was used to estimate the odds ratio (OR) and interaction for survival to hospital discharge in the OCCPR group and the CCCPR group.

We performed instrumental variable analysis, which is an established technique used to control unmeasured confounding in nonrandomized data [19], as the sensitivity analysis for the propensity score matching. This approach was conducted using a two-stage least-squares regression analysis adjusted by following variables: year of injury, sex, TRISS, systolic blood pressure at the scene of injury, and AIS of head, chest, abdomen, and pelvis and lower extremities, on multiply imputed and not propensity score-matched dataset. The mean number of registered patients per year in the hospital was also incorporated into the model as a measure of quality of trauma care provided by the hospital [20]. Issues with variable multicollinearity were assessed by variance inflation factor (VIF) analysis and the tolerance value was set at <2. We selected the variable of “the mean number of OCCPR cases per year in the hospital” as the instrumental variable. The null hypothesis was that there was no association between the mean number of OCCPR cases per year in the hospital and the actual implementation of OCCPR. A partial F test was conducted to assess an issue of weak instruments, and a value of F-statistic >10 was regarded as acceptable. The level of significance was defined as p < 0.05 for all statistical analyses.

Results

Study population

The flow diagram of the patient selection process is shown in Fig. 1. A total of 6510 patients who received CPR in the ED were identified and divided into the OCCPR group (n = 2192) and the CCCPR group (n = 4318), from which 1804 propensity-score-matched pairs were generated.
Fig. 1

Patient selection. JTDB Japan Trauma Databank, AIS abbreviated injury scale, OCCPR open-chest cardiopulmonary resuscitation, CCCPR closed-chest cardiopulmonary resuscitation

Patient characteristics

The baseline characteristics of the multiply imputed dataset before and after propensity score matching is shown in Table 1. The distribution of naïve data and the proportions of missing values are shown in Additional file 2.
Table 1

Baseline characteristics of the multiply imputed dataset before and after propensity score matching

 

Unmatched cohort

Matched cohort

Variables

Open-chest

CPR

Closed-chest CPR

SMD

Open-chest

CPR

Closed-chest CPR

SMD

Number of subjects

2192

4318

 

1804

1825

 

Age (years)

52 (34–68)

56 (36–73)

0.12

52 (34–68)

53 (34–71)

0.05

Sex, male, n (%)

1533 (69.9)

2865 (66.4)

0.08

1250 (69.3)

1248 (69.2)

0.00

Year of Injury, n (%)

 2004

65 (3.0)

170 (3.9)

0.05

63 (3.5)

63 (3.5)

0.00

 2005

58 (2.6)

181 (4.2)

0.08

56 (3.1)

57 (3.1)

0.00

 2006

77 (3.5)

168 (3.9)

0.02

75 (4.2)

56 (3.1)

0.06

 2007

106 (4.8)

323 (7.5)

0.11

100 (5.5)

94 (5.2)

0.01

 2008

155 (7.1)

319 (7.4)

0.01

144 (8.0)

126 (7.0)

0.04

 2009

155 (7.1)

313 (7.2)

0.01

144 (8.0)

135 (7.5)

0.02

 2010

273 (12.5)

468 (10.8)

0.05

249 (13.8)

232 (12.9)

0.03

 2011

240 (10.9)

541 (12.5)

0.05

216 (13.0)

203 (11.3)

0.02

 2012

300 (13.7)

544 (12.6)

0.03

251 (13.9)

251 (13.9)

0.00

 2013

283 (12.9)

542 (12.6)

0.01

223 (12.4)

226 (12.5)

0.01

 2014

267 (12.2)

423 (9.8)

0.08

161 (8.9)

201 (11.1)

0.07

 2015

213 (9.7)

326 (7.5)

0.08

122 (6.8)

160 (8.9)

0.08

Vital signs at the scene of injury

 Systolic blood pressure, mmHg

76 (0–109)

67 (0–107)

0.11

71 (0–107)

68 (0–104)

0.06

 Heart rate, beats/min

60 (0–108)

0 (0–90)

0.28

53 (0–100)

30 (0–100)

0.06

 Respiratory rate, breaths/min

10 (0–24)

0 (0–20)

0.26

6 (0–24)

0 (0–24)

0.05

Cardiac arrest at the scene of injury, n (%)

798 (36.4)

1881 (43.6)

0.15

714 (39.6)

771 (42.7)

0.06

Pre-hospital treatment, n (%)

 Chest compression

1045 (47.7)

2518 (58.3)

0.21

935 (51.8)

943 (52.3)

0.01

 Defibrillation

34 (1.6)

106 (2.5)

0.06

31 (1.7)

36 (2.0)

0.02

Time from EMS dispatch to ED arrival, mins

33 (25–45)

32 (25–42)

0.00

32 (25–44)

32 (25–44)

0.01

Vital signs on ED arrival

 Systolic blood pressure, mmHg

0 (0–40)

0 (0–40)

0.00

0 (0–40)

0 (0–40)

0.01

 Heart rate, beats/min

0 (0–84)

0 (0–60)

0.16

0 (0–75)

0 (0–72)

0.01

 Respiratory rate, breaths/min

0 (0–15)

0 (0–0)

0.14

0 (0–8)

0 (0–10)

0.05

 Body temperature, °C

35.2 (34.2–36.0)

35.2 (34.2–36.1)

0.00

35.2 (34.2–36.0)

35.2 (34.2–36.0)

0.02

Glasgow coma scale on ED arrival

3 (3–3)

3 (3–3)

0.07

3 (3–3)

3 (3–3)

0.02

Revised trauma score on ED arrival

0.00 (0.00–2.34)

0.00 (0.00–1.47)

0.06

0.00 (0.00–1.90)

0.00 (0.00–1.90)

0.00

Cardiac arrest on ED arrival, n (%)

1480 (67.5)

3110 (72.0)

0.10

1266 (70.2)

1272 (70.5)

0.01

Abbreviated injury scale

 Head

0 (0–3)

3 (0–4)

0.47

0 (0–3)

0 (0–3)

0.04

 Face

0 (0–0)

0 (0–0)

0.12

0 (0–0)

0 (0–0)

0.01

 Neck

0 (0–0)

0 (0–0)

0.02

0 (0–0)

0 (0–0)

0.01

 Chest

4 (3–5)

4 (0–5)

0.37

4 (3–5)

4 (3–5)

0.01

 Abdomen

0 (0–2)

0 (0–0)

0.37

0 (0–0)

0 (0–0)

0.02

 Spine

0 (0–0)

0 (0–0)

0.07

0 (0–0)

0 (0–0)

0.00

 Upper extremities

0 (0–0)

0 (0–1)

0.03

0 (0–1)

0 (0–1)

0.01

 Pelvis and lower extremities

2 (0–3)

2 (0–3)

0.14

2 (0–3)

2 (0–3)

0.02

 Surface

0 (0–0)

0 (0–0)

0.09

0 (0–0)

0 (0–0)

0.00

Injury severity score

34 (25–43)

29 (22–41)

0.22

34 (25–43)

34 (25–43)

0.02

Probability of survival, %

3.6 (1.1–14.4)

3.6 (1.2–13.4)

0.01

3.6 (1.2–13.4)

3.6 (1.0–13.4)

0.00

Numeric variables are expressed as median (25th–75th percentiles). Abbreviations: CPR cardiopulmonary resuscitation, SMD standardized mean difference, EMS emergency medical services, ED emergency department

The in-hospital and 24-hour survival rates in the OCCPR group were 1.8% (40/2192) and 5.6% (123/2192), and those in the CCCPR group were 3.6% (156/4318) and 9.6% (416/4318), respectively.

Propensity score matching

The standardized mean difference in the variables according to the estimated propensity score indicated a well-matched balance (Table 1). Of the propensity-score-matched subjects, the proportion of patients surviving to hospital discharge in the OCCPR and CCCPR groups were 1.2% (22/1804) and 3.3% (60/1804), respectively. The proportion of patients in each group surviving over 24 hours after ED arrival were 4.9% (89/1804) and 8.1% (147/1804), respectively. The OCCPR group had significantly lower odds of survival to hospital discharge than the CCCPR group (OR (95% CI) = 0.41 (0.25–0.68)), and the OCCPR group had significantly lower odds of survival over 24 hours after ED arrival than the CCCPR group (OR (95% CI) = 0.59 (0.45–0.79); Table 2).
Table 2

Results of analysis of study outcomes using propensity score matching

Outcomes

Number of patients (%) OCCPR/CCCPR

Odds ratio (95% confidence interval)

P value

Unmatched cohort (OCCPR, 2192 patients; CCCPR, 4318 patients)

 Survival to hospital discharge

40 (1.8)/156 (3.6)

0.49 (0.34–0.71)

<0.001

 Survival over 24 hours after ED arrival

123 (5.6)/416 (9.6)

0.56 (0.45–0.70)

<0.001

Matched cohort (OCCPR, 1804 patients; CCCPR, 1804 patients)

 Survival to hospital discharge

22 (1.2)/60 (3.3)

0.41 (0.25–0.68)

<0.001

 Survival over 24 hours after ED arrival

89 (4.9)/147 (8.1)

0.59 (0.45–0.79)

<0.001

Abbreviations: OCCPR open-chest cardiopulmonary resuscitation, CCCPR closed-chest cardiopulmonary resuscitation, ED emergency department

Survival curve analysis of 30-day mortality was performed (Fig. 2). The log-rank test results revealed significant superiority of CCCPR compared to OCCPR (p < 0.001).
Fig. 2

Kaplan-Meier analysis of 30-day mortality in propensity-score-matched subjects. OCCPR open-chest cardiopulmonary resuscitation, CCCPR closed-chest cardiopulmonary resuscitation

Subgroup analysis

Results of the subgroup analysis are shown in Fig. 3. There were no statistically significant differences between dichotomized subgroups in any variables except for AIS score for pelvic and lower extremity injuries. In patients with severe pelvic and lower extremity injury (AIS score ≥3), OCCPR was significantly associated with a poor outcome compared to CCCPR (p for interaction = 0.038).
Fig. 3

The results of subgroup analysis for the primary outcome. Odds ratios for survival to hospital discharge [95% confidence interval] in each subgroup and p values for interaction between subgroups are presented. OCCPR open-chest cardiopulmonary resuscitation, CCCPR closed-chest cardiopulmonary resuscitation, CI confidence interval, EMS emergency medical services, ED emergency department, ISS injury severity score, AIS abbreviated injury scale

Sensitivity analysis

All of the VIFs of variables used in the linear regression analysis were lower than 2, which eliminated the issue of multicollinearity in our model. The linear regression analysis demonstrated that in one case of an increase in the instrumental variable, there was a significant increase in the proportion of OCCPR implementation (mean difference (95% CI) = 2.9% (2.7, 3.1), F statistic = 74.1); therefore, the null hypothesis that there was no association between the mean number of OCCPR cases per year in the hospital and actual implementation of OCCPR was rejected. However, survival to hospital discharge and survival over 24 hours after ED arrival were not significantly affected by the instrumental variable in the linear regression analysis adjusted by OCCPR (mean difference (95% CI) = 0.0% (−0.0, 0.0) and mean difference (95% CI) = 0.1% (−0.0, 0.2), respectively). Therefore, the variable “the mean number of OCCPR cases per year in the hospital” satisfied the requirements of the instrumental variable in this sensitivity analysis.

The two-way least-squares analysis with this instrumental variable did not alter the original analysis by propensity score matching (mean difference (95% CI) = –5.0% (−9.2, –0.8) for survival to hospital discharge and mean difference (95% CI) = –5.6% (−12.3, 1.1) for survival over 24 hours after ED arrival, respectively; Table 3).
Table 3

Results of instrumental variable analysis of study outcomes

Outcomes

Number of patients (%) OCCPR/CCCPR

Adjusted difference (%) (95% confidence interval)

P value

Survival to hospital discharge

40 (1.8)/156 (3.6)

–5.0 (–9.2, –0.8)

0.019

Survival over 24 hours after ED arrival

123 (5.6)/416 (9.6)

–5.6 (−12.3, 1.1)

0.100

Abbreviations: OCCPR open-chest cardiopulmonary resuscitation, CCCPR closed-chest cardiopulmonary resuscitation, ED emergency department

Discussion

In this nationwide trauma registry, we evaluated the comparative effectiveness of OCCPR in the ED with that of CCCPR in patients with blunt trauma, adjusting for the available patient characteristics. OCCPR was associated with worse rates of survival to hospital discharge and of survival over 24 hours after ED arrival. To our knowledge, there have been no reports comparing OCCPR and CCCPR in patients with cardiac arrest on ED arrival. A prospective randomized controlled trial assessing the comparative effectiveness of OCCPR is not feasible due to ethical concerns; therefore, this analysis of a large database is of significant value in the context of trauma resuscitation.

Although we made strong efforts to control possible biases by incorporating as many available variables as possible into the model and using several statistical techniques, the possibility remained that additional factors not identified in this study potentially influenced clinicians to choose OCCPR instead of CCCPR. If the assumption was valid, patients in the OCCPR group and patients in the CCCPR group would be entirely different cohorts and could not be compared. To evaluate the feasibility of comparing the OCCPR and CCCPR groups, we assessed the proportion of OCCPR implementation among the total CPR cases in each treating hospital. The results showed that the proportion of OCCPR implementation varied greatly depending on each treating hospital (Additional file 3), suggesting that the indications for OCCPR were likely hospital-dependent. It was therefore possible that some patients met the indications for both OCCPR and CCCPR, but were relegated to one group or the other based on the standard operating procedures of the treating hospital. Considering this patient and hospital background, the design of this study that compared the effectiveness of resuscitative approaches (i.e. OCCPR or CCCPR) in patients who met the indications for both OCCPR and CCCPR was reasonable.

Survival rates among patients with blunt trauma undergoing EDT have been reported as 1.4–1.6% [7, 21]. The 1.8% survival rate among patients undergoing OCCPR in the present study was comparable. Therefore, the population in this study may not be biased in terms of survival rates. The reason for the worse survival rates in patients receiving OCCPR in this study may be partially explained by the fact that OCCPR is more invasive than CCCPR, resulting in an additional insult to a critically injured patient. Another major reason may be the loss of the forward blood flow function caused by the loss of intrathoracic pressure. Direct heart compression without sufficient intrathoracic pressure (i.e. thoracic pump function) may have harmful circulatory effects. Furthermore, the JTDB does not provide information on the duration of CCCPR. Therefore, considering the situation that OCCPR was performed as the second-line therapy following CCCPR, the patients who achieved return of spontaneous circulation over a short period of time with CCCPR only were assigned to the CCCPR group in this study, and it is possible that those patients improved the survival rates of the CCCPR group. The lack of this information is an important limitation to our study.

In the subgroup analysis, despite the theoretical benefit of temporary hemostasis by aortic cross-clamping, OCCPR was associated with decreased survival rates in patients with severe injuries of the pelvis and lower extremities. Furthermore, we could not demonstrate the superiority of OCCPR in patients with severe abdominal injury. In cases of abdominal or pelvic injury, it is possible that temporary hemostasis of distal organs was achieved more effectively by alternative approaches such as resuscitative endovascular balloon occlusion of the aorta or cross-clamping of the abdominal aorta during laparotomy in the CCCPR group. Further characterization of these differences would be useful for identifying patients who would potentially benefit from OCCPR.

In this study, we could not conclude that OCCPR was superior to CCCPR in patients without cardiac arrest on ED arrival, despite this subset of patients being previously described as ideal candidates for OCCPR [21, 22]. This result was consistent with the findings of Suzuki et al. [14]. Occasionally OCCPR is performed as a last resort in patients with catastrophic hemorrhage despite exhaustion of all other hemostatic maneuvers. In most of these cases it is unlikely that OCCPR could result in a favorable outcome. The superiority of OCCPR compared to CCCPR in patients without cardiac arrest on ED arrival may be lower than previously considered.

There are also reports of cases in which patient survival was dependent on OCCPR [23, 24], suggesting the existence of a specific population that may benefit from OCCPR. Although this study analyzed a larger number of patients than in previous studies, there were only 40 survivors after OCCPR. We could not identify the specific subgroups that benefit from OCCPR because of the limited number of survivors, and further studies including more survivors are required.

Our study has several limitations. The study design was retrospective; however, our research question cannot feasibly be assessed in a randomized controlled trial because of the ethical issue. Further, because of the nature of the JTDB, important information, such as data on the duration of CCCPR and data on cardiac rhythm at thoracotomy, which were considered important predictors in other reports [25, 26], were unavailable. The data on neurological outcome, which is the ultimate outcome of CPR, was also unavailable in the JTDB. In addition, there was some degree of missing data in the JTDB, particularly on pre-hospital vital signs (Additional file 2). Although our methodology in handling missing data was considered reasonable and statistically appropriate, the results should be interpreted with caution owing to the missing data. Despite these limitations, our well-designed retrospective study provided notable insight into the field of trauma resuscitation, as the comparative effectiveness of OCCPR and CCCPR have never been reported.

Conclusions

OCCPR was associated with reduced rates of survival to hospital discharge and of survival over 24 hours after ED arrival in patients with blunt trauma; and the study could not identify a specific subpopulation that would benefit from OCCPR. Further comparisons between OCCPR and CCCPR with larger numbers of patients, using additional information, such as time course details in pre-hospital and in ED settings, anatomical details on the region of injury, and neurological outcomes, are necessary.

Abbreviations

AIS: 

Abbreviated injury scale

CCCPR: 

Closed-chest cardiopulmonary resuscitation

CI: 

Confidence interval

CPR: 

Cardiopulmonary resuscitation

ED: 

Emergency department

EDT: 

Emergency department thoracotomy

EMS: 

Emergency medical system

GCS: 

Glasgow coma scale

ISS: 

Injury severity score

JTDB: 

Japan Trauma Data Bank

OCCPR: 

Open-chest cardiopulmonary resuscitation

OR: 

Odds ratio

TRISS: 

Trauma and injury severity score

VIF: 

Variance inflation factor

Declarations

Acknowledgements

We gratefully acknowledge Koichiro Gibo, (MD, Department of Emergency Medicine, Okinawa Prefectural Chubu Hospital) who evaluated the validity of the statistical design, approach, and inferences as an expert at handling missing data.

Funding

AS received the Grants-in-Aid for Scientific Research (#24592731) from the Japan Society for the Promotion of Science. Remaining authors: none.

Availability of data and materials

An overview of the JTDB is available at http://www.jtcr-jatec.org/traumabank/index.htm. The detailed data in the JTDB that support the findings of this study are available from Japan Trauma Care and Research but restrictions apply to the availability of these data, which were used under license for the current study, and so are not publicly available.

Authors’ contributions

AE: drafting/revising the manuscript, study concept and design, statistical analysis and interpretation of data, accepts responsibility for conduct of research and final approval, and study supervision. AS: revising the manuscript, study concept and design, acquisition of data, statistical analysis and interpretation of data, accepts responsibility for conduct of research and final approval, and obtaining funding. YO: revising the manuscript, interpretation of data, accepts responsibility for conduct of research, and final approval. MT: revising the manuscript, statistical analysis and interpretation of data, accepts responsibility for conduct of research, and final approval. HM: revising the manuscript, statistical analysis and interpretation of data, accepts responsibility for conduct of research, and final approval. KM: revising the manuscript, interpretation of data, accepts responsibility for conduct of research, and final approval. All authors read and approved the final manuscript.

Ethics approval and consent to participate

The ethics committee of Tokyo Medical and Dental University approved this study (#2192). Informed consent for each patient was waived because of the anonymous nature of the data.

Consent for publication

Not applicable.

Competing interests

The authors declare that they have no competing interests.

Publisher’s Note

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Open AccessThis article is distributed under the terms of the Creative Commons Attribution 4.0 International License (http://creativecommons.org/licenses/by/4.0/), which permits unrestricted use, distribution, and reproduction in any medium, provided you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license, and indicate if changes were made. The Creative Commons Public Domain Dedication waiver (http://creativecommons.org/publicdomain/zero/1.0/) applies to the data made available in this article, unless otherwise stated.

Authors’ Affiliations

(1)
Trauma and Acute Critical Care Medical Center, Hospital of Medicine, Tokyo Medical and Dental University
(2)
Emergency and Trauma Center, Kameda Medical Center
(3)
Clinical Research Center, Hospital of Medicine, Tokyo Medical and Dental University
(4)
Department of Clinical Epidemiology and Health Economics, School of Public Health, University of Tokyo

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Copyright

© The Author(s). 2017

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