| Literature DB >> 31343454 |
William V Padula, Madhuram Nagarajan1, Patricia M Davidson2, Peter J Pronovost3.
Abstract
OBJECTIVES: Hospitals can reduce labor costs by hiring lowest skill possible for the job, stretching clinical hours, and reducing staff not at bedside. However, these labor constraints designed to reduce costs may paradoxically increase costs. Specialty staff, such as board-certified clinicians, can redesign health systems to evaluate the needs of complex patients and prevent complications. The aim of the study was to evaluate whether investing in skilled specialists for supporting hospital quality infrastructure improves value and performance.Entities:
Mesh:
Year: 2021 PMID: 31343454 PMCID: PMC7781087 DOI: 10.1097/PTS.0000000000000623
Source DB: PubMed Journal: J Patient Saf ISSN: 1549-8417 Impact factor: 2.243
FIGURE 1Hypothesized relationship between the ratio of bedside staff and hospital volume relative to performance (e.g., safety and quality indicators). For instance, (A) the size of the hospital (total hospital beds) is directly proportional to the number of bedside nurses (RNs) and certified nurses (e.g., CWCNs). Compared with a standard ratio of bedside nurses, Y0, the nurse-to-bed ratio may shift depending on the perception that an increased investment in infrastructure results in better patient care, Y1. Alternatively, hospitals that have good structure in place to implement practice guidelines efficiently may be able to operate on a more efficient infrastructure, Y2, including fewer bedside staff; however, consolidating infrastructure without putting efficient processes in place for guideline compliance can lead to poorer outcomes. B, Our theory suggests that increased investment in hospital infrastructure in terms of skilled specialists is associated with increased performance, such as reductions in hospital-acquired pressure injury rates, Y. Additional investments in technology and other quality improvement programs that enhance the efficiency of nursing performance (e.g., new bed technology) shifts productivity toward Y′, but only marginally over a baseline investment to increased staff-to-bed ratios.
Average Number of CWCNs Per 1000 Hospital Beds in AMCs in the United States, Stratified by Performance Quintile According to Hospital-Acquired Pressure Injury Rate*
| Average No. CWCNs per 1000 Beds | 3.8† |
|---|---|
| CWCNs per 1000 beds by pressure injury rate quintile | |
| First quintile (0%–20%) | 5.88 |
| Second quintile (21%–40%) | 3.56 |
| Third quintile (41%–60%) | 5.47 |
| Fourth quintile (61%–80%) | 6.81 |
| Fifth quintile (81%–100%) | 5.44 |
*AMCs in the 1st quintile represent the lowest performers (i.e., high or poor rates of pressure injury), and the 5th quintile represents the highest performers (i.e., low or exceptional rates of pressure injury).
†Adjusted for case-mix index and ANCC Magnet Recognition.
FIGURE 2Boxplots of the mean and 25th- to 75th-percentile range of CWCN-bed ratios in AMCs by quintile of pressure ulcer rates, along with outliers represented dots outside of the 95% confidence interval. Overlayed Lowess smoothed curves illustrates the trend of increasing workforce infrastructure with CWCNs between the 1st to 2nd, 3rd, and 4th to 5th quintiles, noting that the highest performing interquintile space is able implement pressure injury prevention strategies with greater efficiency (i.e., fewer CWCNs per 1000 beds).
Relationship Between Hospital-Acquired Pressure Ulcer Rates and the Ratios of CWCNs to Beds, While Controlling for Other Hospital Factors
| Pressure Ulcer Factors | Coefficient (95% CI) | |
|---|---|---|
| CWCN | 0.404 (0.13 to 0.67) | 0.003 |
| Beds | −0.002 (−0.003 to −0.001) | 0.033 |
| Ratio of CWCNs per 1000 beds | −0.177 (−0.31 to −0.04) | 0.009 |
| Magnet status | −0.445 (−0.72 to −0.16) | 0.002 |
| Case-mix index | 0.634 (0.33 to 0.94) | <0.001 |
| CMS policy | −2.176 (−2.29 to −2.06) | <0.001 |
| Intercept | −5.248 (−6.27 to −4.23) | <0.001 |
| Variance (intercept)* | 0.266 (0.17 to 0.41) | <0.001 |
Coefficients were derived from a mixed-effects negative binomial regression model with random intercept measuring pressure injury rates between hospital quarters from 2007 to 2012.
Log likelihood (goodness of fit) = −2153.52.
*A random intercept model was selected over a fixed effects model by way of the Hausman test.
CMS policy, decreases in reimbursement for hospital-acquired conditions in October, 2008; magnet status, hospital designation in the ANCC Magnet Recognition Program.