Survival and Prognostic Factors After Surgery in Single Spinal Metastasis: Comparison of Isolated-Single Spinal Metastasis and Single Spinal Metastasis With Other Metastasis

Abstract

Study Design

Retrospective cohort study.

Objectives

This study aimed to evaluate the survival period in patients with a single spinal metastasis (SSM), subsequently comparing those with isolated-single spinal metastasis (I-SSM) and single spinal metastasis with other metastasis (O-SSM) after surgery, and to identify prognostic factors affecting their survival.

Methods

A total of 135 patients were included, with 24 patients in the I-SSM group and 111 in the O-SSM group. Survival analysis was utilized to assess the survival of SSM patients, followed by a comparison of survival rates between the two groups. Univariate and multivariate analyses were conducted to identify significant prognostic factors for survival.

Results

The overall median survival period for patients with single spinal metastasis (SSM) was 10.2 ± 1.8 months. Specifically, the median survival was 15.7 ± 5.7 months in the I-SSM group and 10.2 ± 1.5 months in the O-SSM group. The difference in survival periods between the two groups was not statistically significant (P = 0.345). Significant independent prognostic factors for survival included preoperative Karnofsky Performance Status (KPS) of 50 – 70 (OR 0.51, P = 0.017) and 80 – 100 (OR 0.46, P = 0.012), postoperative ambulatory status (OR 1.19, P = 0.028), and primary malignancy site [Group B (OR 2.67, P = 0.021), Group C (OR 2.90, P = 0.016)].

Conclusions

Patients with SSM have a median survival of 10.2 months, with no significant difference in postoperative survival between the I-SSM and O-SSM groups. Significant prognostic factors influencing the survival period after surgery include preoperative KPS, postoperative ambulatory status, and the primary malignancy site.

Keywords

single spinal metastasis isolated-single spinal metastasis organ metastasis survival prognostic factors

Introduction

The spine is the most common site of bone metastasis, with nearly one-third of all bone metastases occurring in the spine.^1,2 Spinal metastasis frequently leads to deterioration of spinal structure and cord compression, necessitating appropriate treatment modality.^3,4 Despite remarkable advancements in immunotherapy, targeted therapy, and radiotherapy in recent decades, surgery still plays a critical role in the treatment of metastatic spinal tumors, especially in situations of spinal instability and cord compression.^5-9

When determining the appropriate surgical approach for spinal metastasis, life expectancy is a significant consideration.^9-11 In previous studies, Tokuhashi et al,¹² Tomita et al,¹⁰ and Sioutos et al.¹³ have introduced a scoring system to predict the survival period for patients with spinal metastases. In this scoring system, extensive tumor involvement suggests a larger tumor burden and generally results in a shorter anticipated lifespan.¹⁴ Therefore, even if in single spinal metastasis (SSM), if there are multiple metastases to other organs, palliative surgery tends to be performed because it is believed to have a relatively poor prognosis with a comparatively short life expectancy.^2,12,15 Conversely, an isolated SSM without involvement of other organs may potentially warrant more aggressive surgical interventions such as total en-bloc spondylectomy, given the possibility of a more favorable prognosis.^16-18 However, current research on survival outcomes in patients with SSM is still limited, and it is not well understood whether there exists a difference in survival between patients with isolated-single spinal metastases (I-SSM) and those with SSM involving metastases to other organs (O-SSM).

Therefore, the purpose of this study is to evaluate postoperative survival in patients with SSM, and subsequently compare I-SSM to O-SSM groups, and to identify prognostic factors that exert significant influence on the survival of patients with SSM after surgery.

Materials and Methods

Study Design

The study was approved by the Institutional Review Board of Samsung Medical Center (IRB No. 2023-12-120), and informed consent was waived due to the retrospective nature of the data. We reviewed the medical records of patients who underwent surgery for SSM at our institution between September 2015 and December 2021. The indications for surgical treatment were carefully determined through a multilateral, inter-department conference based on the following criteria: 1) refractory pain despite conservative treatment, and 2) neurological deterioration or the potential for neurological deficits with spinal column instability.

The inclusion criteria in this study cohort were as follows: 1) confirmed diagnosis of SSM based on radiological findings; 2) meeting the criteria for surgery; 3) patients who have been consecutively treated at our institution and followed up for at least 3 months. Meanwhile, patients with multiple spinal metastases, those with life expectancies of less than 3 months, and those with poor medical conditions deemed unable to tolerate surgery by three spine surgeons were excluded.

In this study, SSM was confirmed by radiology specialists at our institution following comprehensive imaging studies, including whole-spine magnetic resonance imaging (MRI), computed tomography (CT) of the chest, abdomen, and pelvis, and whole-body PET-CT. SSM is defined as a primary tumor found elsewhere in the body, not originating in the spine, with metastasis to one vertebral body in the whole spine. I-SSM refers to cases where there is no metastasis to other organs, and metastasis occurs in only one vertebra throughout the whole spine. On the other hand, O-SSM refers to cases where there is metastasis to one vertebral body in the whole spine, along with metastases to other internal organs.

Patients with SSM were categorized into I-SSM and O-SSM groups. Baseline data and potential survival-related variables were compared between these groups to identify any significant differences. Additionally, among patients who were ambulatory postoperatively, we compared I-SSM and O-SSM group patients based on whether they received chemotherapy or not. Survival analysis was performed to assess the overall survival of SSM patients and to determine if there was a difference in survival rates between the two groups. Furthermore, prognostic factors for SSM (including both I-SSM and O-SSM) were investigated to identify variables significantly influencing survival.

Baseline Data and Presumed Survival-Related Factors

This study evaluated various presumed survival-related factors as follows: 1) neurological deficits (Frankel grade) which categorized patients into 3 subgroups (A-B, C-D, and E),^19,20 2) preoperative Karnofsky Performance Scale (KPS), scores were grouped into three categories (10-40, 50-70, and 80-100),^6,21 3) pre- and postoperative ambulatory status,²² 4) primary malignancy site factor using Tomita’s scoring system categorized into Groups A (slow growth), Group B (moderate growth), and Group C (rapid growth),¹⁰ 5) four surgical types: Type 1, fixation only; Type 2, laminectomy and fixation; Type 3, partial corpectomy and fixation; and Type 4, total corpectomy and total en-bloc spondylectomy, 6) modified Tokuhashi score, 7) the presence of major internal organ metastases, and the presence of other bone metastasis, 8) adjuvant chemotherapy and radiation therapy before and after surgery.

Statistical Analysis

To compare the presumed risk factors between I-SSM and O-SSM, the chi-squared test and Fisher’s exact test were conducted, and survival differences between the two groups were assessed using Kaplan-Meier survival analysis. To investigate significant survival-related factors in patients with single spinal metastasis, a univariate analysis using the Log-rank test was conducted. Following this, a multivariate analysis was performed using the Cox proportional hazards model. All statistical evaluations were executed using SPSS software (version 22.0.0; IBM Corp.), with a threshold of P < 0.05 denoting statistical significance.

Results

Baseline Data and Presumed Survival-Related Factors

A total of 135 patients with SSM were included in this study according to inclusion criteria. Twenty-four (17.8%) were classified as I-SSM group, while 111 (82.2%) were classified as O-SSM group. There were 80 men and 55 women with a mean age of 61.3 years. Age and gender showed no significant differences between the two groups. Smoking history was evaluated in 66 (48.9%) of overall patients; however, the difference between the two groups was not statistically significant [10 (41.7%) vs 56 (50.5%), P = 0.435]. There were also no significant differences in the distribution of several potential prognostic factors: neurological deficits (Frankel grade), preoperative KPS, pre- and postoperative ambulatory status, primary malignancy site, administration of chemotherapy and/or radiotherapy before and after surgery, and surgical procedure types. However, the overall mean of the Tokuhashi scores of patients with SSM was 7.84 ± 1.84, with a significant difference between the I-SSM and O-SSM groups: 9.33 ± 1.61 and 7.51 ± 1.73, respectively (P < 0.001) (Table 1).

Table 1.

Comparison of the Baseline Data and Presumed Survival-Related Factors Between I-SSM and O-SSM Groups.

Variables	SSM (N = 135)	I-SSM (N = 24)	O-SSM (N = 111)	P ^*
Patients-related factors
Age (years)	61.3 ± 9.8	62.6 ± 8.7	61.1 ± 10.1	0.482
Sex				0.415
Male	80	16	64
Female	55	8	47
Smoking history^a (%)	66 (48.9%)	10 (41.7%)	56 (50.5%)	0.435
Neurological deficits (Frankel grade)				0.711
A or B	9	2	7
C or D	49	7	42
E	77	15	62
Preoperative KPS				0.346
10 – 40	31	3	31
50 – 70	59	13	46
80 – 100	45	8	37
Preoperative ambulatory status				0.193
Able	98	20	78
Unable	37	4	33
Postoperative ambulatory status				0.170
Able	118	23	95
Unable	17	1	16
Primary malignancy Site factor^b				0.223
Group A (slow growth)	14	3	11
Group B (moderate growth)	29	2	27
Group C (rapid growth)	92	19	73
Surgical procedure type^c				0.070
1	27	9	18
2	52	6	46
3	28	3	25
4	28	6	22
Modified Tokuhashi scor e	7.84 ± 1.84	9.33 ± 1.61	7.51 ± 1.73	<0.001
Adjuvant therapy
Radiotherapy
Before surgery	67	10	57	0.192
After surgery	69	13	56	0.686
Both before and after surgery	27	4	23	0.448
Chemotherapy
Before surgery	60	9	51	0.252
After surgery	64	12	52	0.896
Both before and after surgery	33	6	27	0.565
Postoperative ambulatory status (able)	N = 118			0.886
Chemotherapy after surgery	63	12	51
Non-chemotherapy after surgery	55	11	44

Data are presented as the median ±standard deviation or as the number of patients.

* Bold P-values indicate statistical significance between I-SSM and O-SSM.

^aSmoking history refers to the number of patients who have ever smoked.

^bPrimary malignancy site factor: primary malignancy growth rate using the Tomita’s scoring system.

^cSurgical procedure type: 1, fixation only; 2, laminectomy and fixation; 3, partial corpectomy and fixation; and 4, total corpectomy, total en-bloc spondylectomy, and fixation.

KPS, Karnofsky Performance Status.

Overall Survival of Patients with SSM and Within Groups Between I-SSM and O-SSM

Kaplan-Meier survival analysis revealed a median survival of 10.2 ± 1.8 months (95% confidence interval [CI] 6.8 to 13.6) and a mean survival of 23.3 ± 2.6 months (95% CI 18.2 to 28.4) for all patients with SSM. The overall cumulative survival rate at 12 months was 48.2%, and it further declined to 29.9% at 24 months (Figure 1).

Figure 1.

Kaplan-Meier survival curve in patients with SSM.

Within the groups, the I-SSM patients had a median survival of 15.7 ± 5.7 months (95% CI 4.5 to 26.8) and a mean survival of 29.9 ± 7.8 months (95% CI 14.5 to 45.3). The O-SSM group had a median survival of 10.2 ± 1.5 months (95% CI 7.1 to 13.2) and a mean survival of 21.2 ± 2.4 months (95% CI 16.5 to 26.0). However, these differences were not statistically significant (P = 0.345) (Table 2, Figure 2).

Table 2.

Survival Analysis of Patients With SSM and Comparison Between Patients With I-SSM and Those With O-SSM.

	Survival Period (months)
	SSM
Median (95% CI)	10.2 ± 1.8 (6.8 to 13.6)
Mean (95% CI)	23.3 ± 2.6 (6.8 to 13.6)
	I-SSM	O-SSM	P ^a
Median (95% CI)	15.7 ± 5.7 (4.5 to 26.8)	10.2 ± 1.5 (7.1 to 13.2)	0.345
Mean (95% CI)	29.9 ± 7.8 (14.5 to 45.3)	21.2 ± 2.4 (16.5 to 26.0)	0.345

CI, confidence interval; SSM, single spinal metastasis; I-SSM, isolated-single spinal metastasis; O-SSM, single spinal metastasis with other metastasis.

^aLog-rank test.

Figure 2.

Kaplan-Meier survival analysis for overall survival between patients with I-SSM and those with O-SSM.

Prognostic Factors for Survival After Surgery

Univariate analysis revealed that certain factors did not appear to significantly influence survival: age over 65 years, sex, presence of major internal organ metastases or other bone metastases, and surgical procedure type (Table 3). However, several other factors emerged as potentially meaningful. In terms of preoperative neurological deficits, patients in subgroups A and B (nine individuals) had similar survival, while those in subgroups C and D (49 individuals) and subgroup E (77 individuals) displayed significant differences across subgroups (P = 0.002). In terms of preoperative KPS, the three KPS groups also showed significant differences in survival (P < 0.001). Furthermore, both pre- and postoperative ambulatory status proved to be significant prognostic factors. Notably, patients who could ambulate independently, categorized as the “able” group, demonstrated significantly better survival rates compared to those in the “unable” group (preoperative: median survival time of 14.1 ± 3.1 months vs 5.2 ± 1.0 months, P = 0.001; postoperative: median survival times of 12.9 ± 2.8 months vs 2.8 ± 1.1 months, P < 0.001). The distribution of primary malignancy sites across subgroups A-C (14, 29, and 92 patients, respectively) showed a significant difference in median survival (P = 0.047). Lastly, while most adjuvant therapies did not show significant differences in survival, one exception was postoperative chemotherapy. Patients who received postoperative chemotherapy (64 patients, 47.4%) demonstrated significantly longer survival compared to those who did not (71 patients, 52.6%), with median survival times of 17.6 ± 3.8 months and 7.3 ± 1.8 months, respectively (P = 0.001) (Table 3).

Table 3.

Univariate Analysis of the Presumed Prognostic Factors for Survival.

Variables		N (%)	Median Survival (months)	P ^*
Patients-related factors
Age (years)				0.614
≥65		50 (37.0%)	15.9 ± 16.8
<65		85 (63.0%)	17.6 ± 20.1
Sex				0.877
Male		80 (59.3%)	11.3 ± 2.3
Female		55 (40.7%)	10.1 ± 2.6
Neurological deficits (Frankel grade)				0.002
A or B		9 (6.7%)	4.9 ± 1.0
C or D		49 (36.3%)	6.6 ± 1.9
E		77 (57.0%)	15.7 ± 2.2
Preoperative KPS				<0.001
10 – 40		31 (23.0%)	4.9 ± 1.3
50 – 70		59 (43.7%)	9.8 ± 2.4
80 – 100		45 (33.3%)	16.2 ± 3.0
Preoperative ambulatory status				0.001
Able		98 (72.6%)	14.1 ± 3.1
Unable		37 (27.4%)	5.2 ± 1.0
Postoperative ambulatory status				<0.001
Able		118 (87.4%)	12.9 ± 2.8
Unable		17 (12.6%)	2.8 ± 1.1
Primary malignancy Site facto r ^a				0.047
Group A (slow growth)		14 (10.4%)	27.6 ± 6.2
Group B (moderate growth)		29 (21.5%)	10.1 ± 3.8
Group C (rapid growth)		92 (68.1%)	9.3 ± 1.4
Primary malignancy burden
Major internal organ metastasis				0.139
Yes		64 (47.4%)	9.6 ± 2.0
No		71 (52.6%)	13.6 ± 3.3
Other bone metastasis				0.108
Yes		44 (32.6%)	7.5 ± 1.8
No		91 (67.4%)	13.6 ± 3.3
Surgical procedure type^b				0.279
1		27 (20.0%)	18.2 ± 4.9
2		52 (38.5%)	9.5 ± 1.6
3		28 (20.7%)	8.8 ± 2.5
4		28 (20.7%)	14.1 ± 3.5
Adjuvant therapy
Radiotherapy
Before surgery	Yes	67 (49.6%)	12.9 ± 3.1	0.589
Before surgery	No	68 (50.4%)	9.3 ± 2.0	0.589
After surgery	Yes	69 (51.1%)	9.7 ± 1.6	0.144
After surgery	No	66 (48.9%)	12.8 ± 5.3	0.144
Chemotherapy
Before surgery	Yes	60 (44.4%)	7.0 ± 1.8	0.097
Before surgery	No	75 (55.6%)	13.5 ± 2.7	0.097
After surgery	Yes	64 (47.4%)	17.6 ± 3.8	0.001
After surgery	No	71 (52.6%)	7.3 ± 1.8	0.001

Data are presented as the median ±SD or as the number of patients or as the number of patients (percentage).

* Bold P-values indicate statistical significance.

^aPrimary malignancy site factor: primary malignancy growth rate using the Tomita’s scoring system.

^bSurgical procedure type: 1, fixation only; 2, laminectomy and fixation; 3, partial corpectomy and fixation; and 4, total corpectomy, total en-bloc spondylectomy, and fixation KPS, Karnofsky Performance Status.

A multivariate analysis revealed that patients with higher KPS scores were more likely to survive longer (odds ratio [OR] 0.50, P = 0.007). Additionally, the ability to walk independently after surgery emerged as an independent prognostic factor (OR 2.09, P = 0.028). Furthermore, primary malignancy site group B (OR 2.63, P = 0.031) and group C (OR 2.43, P = 0.029) also show prognostic significance for survival (Table 4).

Table 4.

Multivariate Analysis for Prognostic Factors of Survival in Patients With SSM.

	OR	95% CI	P*
Neurological deficits (Frankel grade)	0.62	0.27-1.45	0.269
Preoperative KPS
10 – 40	1	Reference
50 – 70	0.51	0.30 – 0.89	0.017
80 – 100	0.46	0.26 – 0.84	0.012
Preoperative ambulatory status	1.19	0.66 – 2.14	0.568
Postoperative ambulatory status	2.08	1.08 – 4.00	0.028
Primary malignancy site factor^a
Group A (slow)	1	Reference
Group B (moderate)	2.67	1.20 – 5.96	0.021
Group C (rapid)	2.90	1.17 – 7.16	0.016
Postoperative CTx	0.64	0.39 – 1.04	0.073

OR, Odds ratio; CI, confidence interval; KPS, Karnofsky Performance Status.

* Bold P-values indicate statistical significance.

^aPrimary malignancy site factor: primary malignancy growth rate using the Tomita’s scoring system.

Discussion

Surgical decision-making in SSM remains challenging despite advances in radiotherapy, targeted therapy, and immunotherapy.²³ This study aimed to guide surgeons in navigating the dilemma of surgical aggressiveness for SSM patients. However, the inherent heterogeneity of this population further complicates decision-making, especially considering the limited lifespan associated with SSM. Existing research underscores the short median survival for patients with SSM. Yang et al reported 6 months,²² Lun et al. 8.2 months in 78 patients,¹⁴ and Lee et al. 10.8 months in 200 patients.²⁴ Our study aligns with these findings, revealing a median survival of 10.2 months. This indicates that the median survival for patients with an SSM is relatively short, typically around 12 months. Moreover, Arrigo et al and Bollen et al documented similar median survival times (8.0 and 10.7 months, respectively) even in cohorts including patients without visceral metastases.^25,26 This consistently calls into question whether the presence of visceral metastases should be a definitive factor in surgical decision-making for SSM.

Recent studies have challenged traditional prognostic factors for spinal metastasis, emphasizing the importance of patient’s general health and functional status over previously considered factors. Arrigo et al and Chong et al found that visceral metastasis, generally considered important for prognosis, was not significant for surgically treated patients.^26,27 Lun et al¹⁴ reported no difference in survival between patients with single vs multiple spinal metastases, suggesting that the number of metastases may not impact prognosis. Instead, Switlyk et al and Chen et al identified serum albumin and lactate dehydrogenase levels as significant indicators of general condition and survival prognosis.^21,28 Our study aligns with these findings, identifying preoperative KPS and postoperative ambulatory status as significant prognostic factors, surpassing even visceral metastasis or the number of metastases. Notably, KPS is significant as a preoperative assessment tool that can be used to determine the aggressiveness of surgical intervention.

Ambulatory status is closely linked to KPS, and in non-ambulatory patients, the risks associated with chemotherapy often outweigh its potential benefits due to an increased risk of adverse effects. Consequently, chemotherapy is generally not administered to non-ambulatory patients at our institution. In this study, postoperative chemotherapy was closely related to ambulatory status and appeared as a factor influencing survival in the univariate analysis but was excluded from the multivariate analysis. We hypothesized that this may be attributed to two factors: 1) postoperative ambulation status may serve as a stronger prognostic factor, reflecting the patient’s overall general condition, 2) patients who were capable of ambulation were more likely to receive aggressive chemotherapy. and 3) even when chemotherapy is administered, it may not uniformly improve survival across all patients, as individual variations in chemotherapy resistance may affect treatment efficacy. Interestingly, patients who were unable to ambulate preoperatively but regained ambulatory function postoperatively had a mean survival of 16.0 ± 4.1 months and a median survival of 9.6 ± 3.4 months. This was not statistically significant (P = 0.075) compared to patients who were ambulatory postoperatively, who had a mean survival of 25.3 ± 2.8 months and a median survival of 12.9 ± 2.9 months. This suggests that regaining ambulatory status postoperatively may be associated with improved survival outcomes. However, while postoperative ambulatory status is an important predictive factor, its limitation lies in the difficulty of assessing it preoperatively. Several studies have shown that if the preoperative lower extremity motor grade is at least grade III,^29-31 or if surgery is performed within 48 h of losing ambulatory ability.³² These findings, combined with our results, suggest that timely surgical intervention in carefully selected cases may be beneficial for improving ambulatory status. Furthermore, if this improvement enables patients to receive chemotherapy, it could potentially contribute to overall survival enhancement.

Finally, the primary malignancy site emerged as another significant prognostic factor that can be assessed preoperatively. This aligns with findings by Constans et al,³³ who reported that primary tumor type influences both survival and quality of short-term outcomes in patients with spinal metastases. This study’s finding regarding visceral metastasis adds a noteworthy counterpoint to existing literature. While previous research has consistently identified their presence as a significant prognostic factor,^25-27,34,35 our analysis among surgically treated patients found no such association. One potential explanation for this discrepancy lies in study populations. Previous studies have included patients who did not undergo surgery, introducing heterogeneity, whereas this study only included patients who underwent surgical treatment. Not all spinal metastases necessitate surgical treatment. However, by the time they can reach that point where surgery is necessary, the tumor burden is substantial, and at that point, the overall performance status and general condition may become more important than the tumor burden itself. From the surgeon’s perspective, whether the primary origin site is well controlled is often not one of the primary concerns. Instead, understanding prognostic factors that assist in determining the extent of surgery at the time of surgery is a greater concern. It is therefore worth noting that there appears to be no significant difference in prognosis between I-SSM and O-SSM groups. This implies that, even in the case of a patient with I-SSM, there may not be an imperative need to consider more aggressive surgical treatment.

There are several limitations to this study. First, the study has a relatively small sample size of 135 patients. We focused on patients with SSM who underwent surgical treatment, which further reduced the number of cases available for analysis. In this study, we used the Tomita score (A, B, or C) for grouping; however, this may not fully reflect the diverse biological characteristics and prognoses of individual tumor types. Moreover, this study had a high proportion of Group B (21.5%) and Group C (68.1%), which together constitute a larger fraction (89.6%) compared to Group A (10.4%). This uneven distribution may be due to differences in racial, genetic, lifestyle, and dietary factors. Additionally, because this study focused on patients who underwent surgical treatment, there might be a tendency toward including more aggressive tumor types. Consequently, the findings may not be generalizable to other geographic locations. Future studies with larger cohorts might benefit from analyzing survival and prognostic factors specific to particular tumor types rather than broad categories. Second, there was a lack of data regarding the prognosis of non-surgical patients. Our study aimed to assess postoperative prognosis based on the timing of the need for surgical treatment. Terminal-stage patients with spinal metastases exhibit significant heterogeneity due to varying general conditions and comorbidities, potentially introducing bias in survival data. However, indications for surgical treatment were carefully determined through multidisciplinary collaboration. Therefore, this study is significant for providing valuable insights into prognostic factors relevant to determining the appropriate extent of surgical treatment, particularly in patients with SSM.

Conclusion

Patients with SSM have a median survival of 10.2 months, with no significant difference in postoperative survival between I-SSM and O-SSM groups. Significant prognostic factors for survival after surgery in SSM patients included preoperative KPS, postoperative ambulatory status, and the primary malignancy site. Therefore, even in the case of I-SSM, aggressive surgery should be undertaken cautiously with careful consideration of these identified factors.

Supplemental Material

Supplemental Material - Survival and Prognostic Factors After Surgery in Single Spinal Metastasis: Comparison of Isolated-Single Spinal Metastasis and Single Spinal Metastasis With Other Metastasis

Supplemental Material for Survival and Prognostic Factors After Surgery in Single Spinal Metastasis: Comparison of Isolated-Single Spinal Metastasis and Single Spinal Metastasis With Other Metastasis by Hyun-Jun Kim, MD, Jin-Sung Park, Se-Jun Park, Dong-Ho Kang, and Chong-Suh Lee in Global Spine Journal

Footnotes

Declaration of Conflicting Interests

The author(s) declared no potential conflicts of interest with respect to the research, authorship, and/or publication of this article.

Funding

The author(s) received no financial support for the research, authorship, and/or publication of this article.

ORCID iDs

Hyun-Jun Kim

Jin-Sung Park

Dong-Ho Kang

Supplemental Material

Supplemental material for this article is available online.

References

Hatrick

Lucas

Timothy

Smith

. The surgical treatment of metastatic disease of the spine. Radiother Oncol. 2000;56:335-339.

Toma

Dominkus

Nedelcu

, et al. Metastatic bone disease: a 36‐year single centre trend‐analysis of patients admitted to a tertiary orthopaedic surgical department. J Surg Oncol. 2007;96:404-410.

Coleman

. Clinical features of metastatic bone disease and risk of skeletal morbidity. Clin Cancer Res. 2006;12:6243s-6249s.

Wong

Fornasier

MacNab

. Spinal metastases: the obvious, the occult, and the impostors. Spine. 1990;15:1-4.

Laufer

Bilsky

. Advances in the treatment of metastatic spine tumors: the future is not what it used to be. J Neurosurg Spine. 2019;30:299-307.

van der Linden

Dijkstra

Vonk

Marijnen

Leer

JWH

Dutch Bone Metastasis Study Group . Prediction of survival in patients with metastases in the spinal column: results based on a randomized trial of radiotherapy. Cancer. 2005;103:320-328.

Jaipanya

Chanplakorn

. Spinal metastasis: narrative reviews of the current evidence and treatment modalities. J Int Med Res. 2022;50:03000605221091665.

Conway

Graham

Kidd

Levack

Scottish Cord Compression Group . What happens to people after malignant cord compression? Survival, function, quality of life, emotional well-being and place of care 1 month after diagnosis. Clin Oncol. 2007;19:56-62.

Hong

Chang

B-S

Kim

Kang

D-H

Chang

. An updated review on the treatment strategy for spinal metastasis from the spine surgeon’s perspective. Asian Spine J. 2022;16:799-811.

10.

Tomita

Kawahara

Kobayashi

Yoshida

Murakami

Akamaru

. Surgical strategy for spinal metastases. Spine. 2001;26:298-306.

11.

Han

Wang

Jiang

, et al. Surgery and survival outcomes of 30 patients with neurological deficit due to clear cell renal cell carcinoma spinal metastases. Eur Spine J. 2015;24:1786-1791.

12.

Tokuhashi

Matsuzaki

Oda

Oshima

Ryu

. A revised scoring system for preoperative evaluation of metastatic spine tumor prognosis. Spine. 2005;30:2186-2191.

13.

Sioutos

Arbit

Meshulam

Galicich

. Spinal metastases from solid tumors. Analysis of factors affecting survival. Cancer. 1995;76:1453-1459.

14.

Lun

Wang

, et al. Prognostic differences in patients with solitary and multiple spinal metastases. Orthop Surg. 2019;11:443-450.

15.

Hinojosa-Gonzalez

Roblesgil-Medrano

Villarreal-Espinosa

, et al. Minimally invasive versus open surgery for spinal metastasis: a systematic review and meta-analysis. Asian Spine J. 2022;16:583-597.

16.

Abe

Sato

Murai

Tazawa

Chiba

Okuyama

. Total spondylectomy for solitary spinal metastasis of the thoracolumbar spine: a preliminary report. Tohoku J Exp Med. 2000;190:33-49.

17.

Sakaura

Hosono

Mukai

Ishii

Yonenobu

Yoshikawa

. Outcome of total en bloc spondylectomy for solitary metastasis of the thoracolumbar spine. J Spinal Disord Tech. 2004;17:297-300.

18.

Wang

Truong

Liberman

, et al. Single-stage posterior approach for the en bloc resection and spinal reconstruction of T4 pancoast tumors invading the spine. Asian Spine J. 2022;16:702-711.

19.

Capaul

Zollinger

Satz

Dietz

Lehmann

Schurch

. Analyses of 94 consecutive spinal cord injury patients using ASIA definition and modified Frankel score classification. Paraplegia. 1994;32:583-587.

20.

Chen

Y-J

Chen

H-T

Hsu

H-C

. Preoperative palsy score has no significant association with survival in non-small-cell lung cancer patients with spinal metastases who undergo spinal surgery. J Orthop Surg Res. 2015;10:149-158.

21.

Switlyk

Kongsgaard

Skjeldal

, et al. Prognostic factors in patients with symptomatic spinal metastases and normal neurological function. Clin Oncol. 2015;27:213-221.

22.

Yang

Cho

Chang

U-K

. Analysis of prognostic factors relating to postoperative survival in spinal metastases. J Korean Neurosurg Soc. 2012;51:127-134.

23.

Byvaltsev

Polkin

Kalinin

, et al. Laminoplasty versus laminectomy in the treatment of primary spinal cord tumors in adult patients: a systematic review and meta-analysis of observational studies. Asian Spine J. 2023;17:595-609.

24.

Lee

Park

J-O

Kim

H-S

Park

Y-C

Lee

H-M

Moon

S-H

. Perioperative complication and surgical outcome in patients with spine metastases: retrospective 200-case series in a single institute. Clin Neurol Neurosurg. 2014;122:80-86.

25.

Bollen

De Ruiter

Pondaag

, et al. Risk factors for survival of 106 surgically treated patients with symptomatic spinal epidural metastases. Eur Spine J. 2013;22:1408-1416.

26.

Arrigo

Kalanithi

Cheng

, et al. Predictors of survival after surgical treatment of spinal metastasis. Neurosurgery. 2011;68:674-681.

27.

Chong

Shin

S-H

Yoo

, et al. Single-stage posterior decompression and stabilization for metastasis of the thoracic spine: prognostic factors for functional outcome and patients' survival. Spine J. 2012;12:1083-1092.

28.

Chen

Xiao

Yang

Zhang

Yuan

. Preoperative scoring systems and prognostic factors for patients with spinal metastases from hepatocellular carcinoma. Spine. 2010;35:E1339-E1346.

29.

Park

Rhim

Jeon

. Efficacy of decompression and fixation for metastatic spinal cord compression: analysis of factors prognostic for survival and postoperative ambulation. J Korean Neurosurg Soc. 2011;50:434-440.

30.

Park

S-J

Park

J-S

Lee

C-S

Kim

H-J

Lee

J-H

. Predictor of postoperative ambulatory recovery in metastatic spinal cord compression with delayed surgical timing and progressive paraplegia. World Neurosurg. 2024;182:e91-e97.

31.

Park

Jeon

. Pre-and postoperative lower extremity motor power and ambulatory status of patients with spinal cord compression due to a metastatic spinal tumor. Spine. 2013;38:E798-E802.

32.

Kinoshita

Kamoda

Hagiwara

Kinoshita

Ohtori

Yonemoto

. Predictors of postoperative gain in ambulatory function after decompressive surgery for metastatic spinal cord compression. Anticancer Res. 2023;43:1767-1773.

33.

Constans

de Divitiis

Donzelli

Spaziante

Meder

Haye

. Spinal metastases with neurological manifestations: review of 600 cases. J Neurosurg. 1983;59:111-118.

34.

Kataoka

Kunisada

Tanaka

, et al. Statistical analysis of prognostic factors for survival in patients with spinal metastasis. Acta Med Okayama. 2012;66:213-219.

35.

Ratasvuori

Wedin

Hansen

, et al. Prognostic role of en‐bloc resection and late onset of bone metastasis in patients with bone‐seeking carcinomas of the kidney, breast, lung, and prostate: SSG study on 672 operated skeletal metastases. J Surg Oncol. 2014;110:360-365.

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