Introduction
Coronary artery disease (CAD) represents a significant public health burden, impacting a substantial global population of 244.11 million individuals and exhibiting the highest fatality rate among all cardiovascular conditions [
1‐
3]. Given the dynamic nature of the CAD process, leading to diverse clinical manifestations, it is conveniently classified into acute coronary syndromes (ACS) and chronic coronary syndromes (CCS), which constitute a substantial proportion of CAD cases [
4]. According to the 2016 data released by the American College of Cardiovascular Diseases, it is projected that by the year 2030, approximately 18% of adults will be affected by CCS, thereby posing a grave concern to the overall well-being of individuals [
5]. Therefore, identifying reliable biomarkers associated with CCS is crucial for early detection, risk assessment, and targeted interventions to prevent or manage the disease. Nonetheless, there exists a scarcity of studies focusing on this specific patient group that utilizes clinically valuable indicators to prognosticate adverse clinical outcomes related to CCS.
The Atherogenic Index of Plasma (AIP) represents a logarithmically transformed quotient of plasma triglycerides (TG) to high-density lipoprotein-cholesterol (HDL-C) (Log (TG/HDL-C)) [
6,
7]. It has demonstrated significant associations with HDL-C, low-density lipoprotein-cholesterol (LDL-C), and very low-density lipoprotein (VLDL) particle sizes, thereby establishing its predictive capability for cardiovascular disease (CVD) risk [
8,
9]. Numerous studies have investigated the association between AIP and various CVD, including ACS, atherosclerosis, and ST-segment elevation myocardial infarction (STEMI) after primary percutaneous coronary intervention (PCI) [
10‐
12]. Zheng et al. demonstrated the utility of AIP in prognosticating outcomes among non-diabetic patients with CAD who had undergone PCI over a two-year follow-up period [
13]. Elevated AIP values have been documented in patients with ACS and have been employed as an indicator to assess the extent of lipid-driven inflammation within this population [
10]. In STEMI patients following PCI, the AIP exhibits superior predictive capabilities in comparison to individual measurements of TG and HDL-C levels [
12]. However, despite the extensive studies on the relationship between AIP and CVD, there is no data specifically examining the association between AIP and patients with CCS. Understanding the potential role of AIP in the pathogenesis and progression of CCS could provide valuable insights into its underlying mechanisms and help identify novel therapeutic targets.
Consequently, the primary objective of this study was to investigate the association between AIP and the likelihood of experiencing major adverse cardiovascular events (MACE) in patients with CCS.
Materials and methods
Study design and population
The present study is a single-center retrospective observational study that was conducted at Shanghai Tenth People’s Hospital from June 2015 to June 2019. A consecutive cohort of 404 subjects admitted for CCS and undergoing coronary angiography (CAG) were recruited for the study. The patients diagnosed with suspected or established CCS according to the 2019 European Society of Cardiology (ESC) guidelines [
4] and aged over 18 years old were enrolled in this study. The major exclusion criteria were consisting of the following items: (1) recent occurrence of myocardial infarction (MI) within 7 days; (2) post coronary artery bypass graft surgery (CABG); (3) severe hepatic or renal insufficiency; (4) malignancy; (5) left ventricular ejection fraction (LVEF) below 35%; (6) presence of other major diseases significantly affecting long-term survival; (7) instances of patient loss to follow-up or incomplete AIP data. Our study was carried out in accordance with the Helsinki Declaration and was approved by the ethical review board of Shanghai Tenth People’s Hospital (ethical number: SHSY-IEC-5.0/23K92/P01). Each participating patient in this study recruited written informed consent.
Data collection and definitions
Baseline demographic data, encompassing variables such as age, gender, height, weight, body mass index (BMI), heart rate, and blood pressure, along with pertinent clinical information, including past medical history (e.g., hypertension, diabetes, hyperlipidemia, atrial fibrillation, smoking, chronic kidney disease (CKD), heart failure, and stroke), coronary angiographic findings, echocardiography parameters, and medication history, were retrospectively acquired from the medical records of all study participants. Laboratory parameters were obtained after an overnight fast via venous blood samples on admission to measure fasting blood glucose (FBG), hemoglobin A1c (HbA1c), total cholesterol (TC), TG, LDL-C, serum creatinine (SCr), C-reactive protein (CRP), alanine aminotransferase (ALT), aspartate aminotransferase (AST), estimated glomerular filtration rate (eGFR), and hemoglobin (Hb) levels. Blood glucose, TC, LDL-C, HDL-C, and TG were analyzed using Abbott Laboratories (Chicago, IL, USA). A diabetes diagnosis is established on the following criteria: (1) FBG ≥ 7.0 mmol/l (≥ 126 mg/dl); (2) Random plasma glucose ≥ 11.1 mmol/l (≥ 200 mg/dl); (3) OGTT glucose level ≥ 11.1 mmol/l (200 mg/dl); and (4) HbA1c ≥ 6.5%. The eGFR was calculated using the Modification of Diet in Renal Disease Study (MDRD) GFR equation. Remnant-C was estimated as total cholesterol minus LDL-C minus HDL-C. Non-HDL-C was calculated as total cholesterol minus HDL-C.
Determination of AIP and grouping
The calculation of AIP is determined by the base 10 logarithms of the ratio of the TG level to HDL-C level in molar concentration (mmol/L), and it is mathematically derived from log (TG/HDL-C) [
14]. Subsequently, all patients were divided into MACE and non-MACE groups as well as the quartile groups based on their AIP values (Q1: < -0.064; Q2: -0.064–0.130; Q3: 0.130–0.328; Q4: > 0.328).
Follow-up and clinical endpoints
In this study, all patients were followed up for a median duration of 35 months. Two trained physicians at Shanghai Tenth People’s Hospital recorded the clinical outcomes via telephone calls, outpatient visits, review of medical case history, and communication with patients’ families. The primary clinical endpoints of the present study were MACE, which is a combination of cardiovascular death, Ischemia-driven revascularization, nonfatal MI, heart failure, and nonfatal stroke. Deaths derived from heart failure, malignant arrhythmias, acute MI, or other cardiac conditions refer to cardiovascular death. Ischemia-driven revascularization was defined as revascularization due to continual angina or a positive test for cardiac ischemia. Nonfatal MI was defined as a composite of notable symptoms of myocardial ischemia, positive cardiac biomarkers, and observable dynamic changes on electrocardiograms [
15]. The diagnosis of heart failure adhered to the latest guidelines provided by the ESC for the diagnosis and management of both acute and chronic heart failure [
16]. The diagnosis of stroke is established based on the presence of cerebral infarction, as ascertained by the manifestation of characteristic clinical symptoms or through imaging examinations [
17].
Statistical analysis
We performed statistical analysis with the use of Statistical Package for Social Sciences (SPSS) v.25., and the figures were generated by GraphPad software 9. Ink. For continuous variables, the variables are displayed as the mean ± standard deviation, while the categorical variables were presented as counts and percentages (%). A t-test or an ANOVA was conducted to compare the continuous variables between groups. Pearson’s chi-squared (χ2) test or Fisher’s exact test, depending on the circumstance, was used to compare categorical variables.
Univariate Cox proportional hazards regression modeling was used to analyze independent clinical risk factors associated with MACE, and the clinical risk factors listed in Table
1 that probably facilitate the risk of adverse outcomes in CCS patients served as the variables in the univariate analysis stratified by the AIP quartile. All the significant covariates with P < 0.10 in the univariate analysis were further selected for the multivariate analysis to determine whether the AIP quartile can be served as the independent predictors for the MACE of the CCS patients, and the estimated hazard ratio (HR) and 95% confidence interval (CI) were applied in the analysis. The Kaplan–Meier method was used for the graphical evaluation of time-related MACE and differences were determined by log-rank tests. The Spearman correlation test was used to seek linear relations between AIP and other clinical risk factors. In addition, the receiver operating curve (ROC) analysis was utilized to calculate their corresponding area under the curve (AUC) and the optimal cut-off value of AIP to predict clinical outcomes according to the Youden index. All analysis was conducted two-sided, and a P-value < 0.05 was considered statistically significant for all analyses.
Table 1
Clinical characteristics of the study population stratified by MACE
General characteristics | | | | |
Age (years) | 63.61 ± 9.64 | 65.52 ± 9.22 | 63.08 ± 9.70 | 0.035 |
BMI (kg/m2) | 25.05 ± 3.14 | 25.47 ± 3.04 | 24.94 ± 3.17 | 0.166 |
h (beats per minute) | 76.70 ± 11.52 | 77.91 ± 10.79 | 76.36 ± 11.71 | 0.266 |
Male, n (%) | 238(58.9) | 55(62.5) | 183(57.9) | 0.439 |
SBP (mmHg) | 134.52 ± 57.29 | 133.71 ± 20.09 | 134.73 ± 63.55 | 0.888 |
DBP (mmHg) | 78.36 ± 12.79 | 77.05 ± 11.57 | 78.70 ± 13.08 | 0.304 |
Comorbidities | | | | |
DM, n (%) | 144(35.6) | 39(44.3) | 105(33.2) | 0.055 |
Hyperlipidemia, n (%) | 127(31.4) | 33(37.5) | 94(29.7) | 0.166 |
Atrial fibrillation, n (%) | 20(4.9) | 6(6.8) | 14(4.4) | 0.525 |
Smoke, n (%) | 83(20.5) | 20(22.7) | 63(19.9) | 0.567 |
Hypertension, n (%) | 254(62.8) | 56(63.6) | 198(62.7) | 0.867 |
Heart failure, n (%) | 5(1.2) | 3(3.4) | 2(0.6) | 0.120 |
CKD, n (%) | 30(7.4) | 9(10.2) | 21(6.6) | 0.257 |
Stroke, n (%) | 62(15.3) | 19(21.6) | 43(13.6) | 0.066 |
PCI conducted, n (%) | 198(49.0) | 43(48.9) | 155(49.1) | 0.622 |
1-vessel disease | 110(27.2) | 24(27.3) | 86(27.2) | 0.991 |
2-vessel disease | 90(22.3) | 21(23.9) | 69(21.8) | 0.686 |
3-vessel disease | 57(14.1) | 16(18.2) | 41(13.0) | 0.215 |
Laboratory parameters | | | | |
TC (mmol/L) | 3.83 ± 1.02 | 3.93 ± 1.06 | 3.80 ± 1.01 | 0.295 |
HDL-C (mmol/L) | 1.09 ± 0.27 | 1.05 ± 0.27 | 1.10 ± 0.27 | 0.137 |
LDL-C (mmol/L) | 2.10 ± 0.90 | 2.17 ± 0.95 | 2.08 ± 0.89 | 0.430 |
TG (mmol/L) | 1.76 ± 1.37 | 1.92 ± 1.46 | 1.71 ± 1.35 | 0.208 |
Remnant-C (mmol/L) | 0.64 ± 0.50 | 0.71 ± 0.43 | 0.62 ± 0.52 | 0.129 |
Non-HDL (mmol/L) | 2.73 ± 0.99 | 2.88 ± 1.00 | 2.69 ± 0.99 | 0.112 |
AIP | 0.15 ± 0.29 | 0.20 ± 0.28 | 0.13 ± 0.30 | 0.039 |
FBG (mmol/L) | 5.75 ± 1.76 | 6.23 ± 2.33 | 5.62 ± 1.55 | 0.025 |
Hb1AC (%) | 6.36 ± 1.20 | 6.53 ± 1.14 | 6.31 ± 1.21 | 0.147 |
CRP (mg/L) | 3.94 ± 6.94 | 4.71 ± 7.14 | 3.71 ± 6.88 | 0.247 |
SCr (umol/L) | 75.21 ± 20.80 | 78.45 ± 17.34 | 74.29 ± 21.62 | 0.097 |
ALT (U/L) | 24.22 ± 17.87 | 27.12 ± 27.61 | 23.41 ± 13.94 | 0.228 |
AST (U/L) | 23.56 ± 18.34 | 28.60 ± 34.86 | 22.13 ± 9.03 | 0.088 |
eGFR (ml/min/l.73 m2) | 103.94 ± 27.35 | 96.82 ± 23.69 | 105.95 ± 28.01 | 0.006 |
Hb (g/L) | 134.02 ± 15.59 | 134.63 ± 14.56 | 133.85 ± 15.89 | 0.682 |
Platelets(x109/L) | 205.37 ± 52.62 | 208.88 ± 54.42 | 204.39 ± 52.16 | 0.480 |
LVEF (%) | 61.88 ± 6.06 | 59.06 ± 9.47 | 62.72 ± 4.29 | 0.001 |
Cardiovascular medical therapy | | | | |
Aspirin, n (%) | 290(71.8) | 56(63.6) | 234(74.1) | 0.055 |
Clopidogrel, n (%) | 228(56.4) | 57(64.8) | 171(54.1) | 0.075 |
Statin, n (%) | 360(89.1) | 79(89.8) | 281(88.9) | 0.821 |
ACEI/ARB, n (%) | 183(45.3) | 49(55.7) | 134(42.4) | 0.027 |
Beta blocker, n (%) | 194(48.0) | 39(44.3) | 155(49.1) | 0.432 |
CCB, n (%) | 160(39.6) | 39(44.3) | 121(38.3) | 0.307 |
Discussion
The present study is the first to examine the correlation between AIP and the prognostic implications for patients with CCS. The novel discoveries from our investigation encompassed the following observations: (1) a significant elevation in AIP levels among patients who experienced MACE in contrast to those who did not encounter such events; (2) elevated AIP level was found to be independently associated with an increased risk of MACE in patients diagnosed with CCS; (3) the AIP emerged as a significant independent risk predictor for CCS patients, with a discernible optimal cut-off value of 0.24 for predicting the occurrence of MACE.
CCS represents a clinical manifestation of CAD characterized by the exclusion of acute coronary thrombosis [
4]. Despite significant developments in the prevention and treatment of atherosclerosis, CAD remains the leading cause of death among the Chinese and global populations, and its incidence is rising and starting earlier in life [
18‐
21]. Given the unfavorable prognosis often associated with the CCS population, the utilization of clinical risk predictors becomes pivotal in identifying CCS patients at heightened risk for new major cardiovascular clinical outcomes. Liu et al. reported that N-terminal pro-brain natriuretic peptide (NT-proBNP) could well predict worse outcomes in dysglycemic patients with CCS and normal left-ventricular systolic function, suggesting that NT-proBNP may help with risk stratification in this population [
22]. Guo et al. suggested that the triglyceride-glucose (TyG) index could be a potent predictor in evaluating the prognosis of CCS patients undergoing PCI, and has shown that increased TyG index was associated with elevated risk for long-term PCI complications, including repeat revascularization and in-stent restenosis [
23]. Our recent study demonstrated TyG index emerged as an independent predictor of MACE among patients with CCS and coronary microvascular dysfunction (CMD) either [
24]. In addition, our recent study highlighted that CMD evaluated through the CAG-derived index of microvascular resistance emerged as a significant and independent predictor of MACE among patients with diabetes diagnosed with CCS [
25]. Notwithstanding, there remains a paucity of research examining the predictive capability of a novel index within the CCS population. Our study identifies a novel predictor of MACE in patients diagnosed with CCS, with the ultimate aim of implementing preventive strategies to impede disease progression.
Elevated triglyceride levels independently raise the risk of atherosclerosis and CCS. Impaired triglyceride metabolism can lead to the formation of atherogenic triglyceride-rich lipoproteins (TRLs) and small, dense LDL particles, promoting atherosclerosis. Impaired triglyceride metabolism is a component of metabolic syndrome, which increases CCS risk. In addition, it is known that higher HDL-C levels are associated with protective effects against atherosclerosis, while higher triglyceride levels are linked to increased cardiovascular risk. Lower HDL-C levels may inhibit the anti-atherogenic properties of HDL, and these lipid profile changes may precede the development of glycemic dysregulation [
26‐
28]. AIP, represented by the logarithm of the ratio of plasma concentrations of TG to HDL-C, is a pivotal index that holds promise as an independent parameter for estimating cardiac risk [
9,
29]. Lipids and their lipoprotein constituents have been identified as both mediators and markers of CAD, denoted by an elevated ratio of LDL-C to HDL-C and an increased level of TG [
30]. Numerous clinical studies have consistently revealed that the AIP exhibits robust predictive potential for adverse outcomes among patients with CVD, thereby positioning it as a noteworthy indicator for atherosclerosis prediction [
11,
31]. Süleymanoğlu et al. revealed that AIP was an independent predictor for no-reflow in patients with acute STEMI who underwent PCI [
12]. Furthermore, multiple investigations have also indicated that the AIP serves as a significant risk factor for CAD in patients diagnosed with type 2 diabetes mellitus (T2DM) [
32,
33]. The study conducted by Wan et al. unveiled that heightened AIP values emerge as a robust and independent prognostic indicator for all-cause mortality and subsequent CVD following coronary revascularization [
34]. Nonetheless, the prognostic significance of AIP within the CCS population remains obscure, rendering the identification of high-risk patients of paramount clinical importance. In accordance with prior investigations, the present study elucidates a strong association between AIP and the risk of MACE in patients diagnosed with CCS. The clinical outcomes of CCS patients exhibiting elevated levels of AIP demonstrated a higher incidence of MACE even following adjustment for other potential confounding risk factors. This underscores the significance of lipid distribution, as evidenced by the AIP index, in the pathophysiological mechanisms underlying CCS [
9]. Significantly, in our investigation, we observed a substantial correlation between the AIP and a range of pertinent variables, including Age, BMI, DBP, FBG, Hb1AC, SCr, TC, HDL-C, LDL-C, and TG, all of which have been previously identified in as relevant risk indicators for CVD [
35‐
42]. These findings underscore the significance of AIP as a determinant of disease severity and its substantial prognostic impact in individuals with CCS.
The determination of a predictive cut-off value for AIP varies across different diseases owing to the diversity in risk factors and pathophysiological mechanisms associated with each specific condition. Prior investigations have conducted multiple studies focusing on the sensitivity and specificity of diverse cut-off values for AIP in patients with CAD [
12,
14,
43‐
46]. Khosravi et al. Reported that utilizing the AIP index alone can serve as an effective predictor of atherogenic plaque instability and the best cut-off value of AIP was 0.62, with a sensitivity of 89.70% and specificity of 34% [
43]. As reported in a previous study, employing a cut-off level of 0.54, the AIP exhibited a sensitivity of 46.02% and a specificity of 84.73% in detecting the no-reflow phenomenon in patients with acute STEMI who underwent PCI [
12]. An additional investigation demonstrated the favorable predictive accuracy of AIP in forecasting post-PCI outcomes in patients with T2DM. Consequently, monitoring AIP levels for lipid management in diabetic patients after PCI is recommended, with the target threshold set at 0.318, as the baseline AIP value of 0.318 was identified as the optimal cut-off point for prognostic risk prediction [
14]. In the investigation by Karadağ et al., it was observed that AIP serves as a predictor of ejection fraction and possesses specific cut-off values for effectively diagnosing heart failure (HF); notably, the identified cut-off level of 0.47 exhibited a sensitivity of 68% and a specificity of 53% in the context of HF diagnosis [
44]. Among patients diagnosed with STEMI, the AIP emerged as a significant marker influencing pre-PCI thrombolysis in myocardial infarction flow; the established cut-off value was determined to be 0.59, with corresponding sensitivity and specificity rates of 67.6% and 68.4%, respectively [
45]. In a recent study investigating prognostic risk factors for acute myocardial infarction (AMI), the optimal cut-off value for the AIP concerning AMI was identified as -0.06142 [
46]. Nevertheless, research regarding the optimal cut-off value of AIP for predicting MACE among patients with CCS remains unknown. Our ROC curve analysis of AIP indicated that the most suitable cut-off value for predicting MACE within the CCS population was 0.24, with an AUC of 0.586. We further divided the patients into a high AIP group and a low AIP group based on our own cut-off value of 0.24; the results show that the MACE rate is higher in the high AIP group (AIP ≥ 0.24) compared to the low AIP group (AIP < 0.24) (Additional file 1: Figure
S2). This finding suggests that the AIP exhibits favorable predictive accuracy concerning prognosis.
Overall, the findings of this study may contribute to the existing body of knowledge on the role of AIP in cardiovascular diseases and provide insights into the potential clinical utility of AIP as a marker for CCS. Ultimately, this study may have implications for improving risk assessment, prevention, and management strategies for patients with CCS, leading to better patient outcomes and reduced burden of the disease.
Study limitations
Several limitations are associated with our study. Firstly, it is important to acknowledge that this research constitutes a single-center retrospective observational study, which inherently imposes certain restrictions on the generalizability of the findings. Secondly, the sample size employed in the study is relatively small, potentially limiting the statistical power and precision of the results. Additionally, the follow-up period of 35 months might be considered relatively short in the context of CCS, possibly affecting the completeness of long-term outcomes. Thirdly, in our study, the lipid parameters employed for calculating the AIP were assessed at the time of admission and not continuously monitored throughout the follow-up period. Moreover, it is essential to acknowledge that all participants in this study are of Chinese ethnicity; although racial homogeneity might be considered an advantage, the findings of this study may not be extrapolated to other ethnic groups without caution. Given the observational nature of the study, we cannot confidently establish definitive conclusions about causative mechanisms and temporal relationships. Despite these limitations, our findings indicate that patients with elevated AIP had an independent relationship with worse prognosis. An elevated AIP value indicates to medical practitioners that patients are more likely to be at a significant risk of metabolic dysfunction. This condition involves a critical concern regarding serum lipid management, necessitating immediate adjustments to their lifestyle. Further studies are required to highlight this association of AIP with MACE in a larger cohort with multi-center prospective studies and elucidate the precise mechanism of AIP in CCS.
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